Financial Stress and Economic Activity: Evidence from a New Worldwide Index
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Hites Ahir
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Mr. Giovanni Dell'Ariccia
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Davide Furceri https://isni.org/isni/0000000404811396 International Monetary Fund

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Mr. Chris Papageorgiou
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Hanbo Qi
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This paper uses text analysis to construct a continuous financial stress index (FSI) for 110 countries over each quarter during the period 1967-2018. It relies on a computer algorithm along with human expert oversight and is thus easy to update. The new indicator has a larger country and time coverage and higher frequency than similar measures focusing on advanced economies. And it complements existing binary chronologies in that it can assess the severity of financial crises. We use the indicator to assess the impact of financial stress on the economy using both country- and firm-level data. Our main findings are fivefold: i) consistent with existing literature, we show an economically significant and persistent relationship between financial stress and output; ii) the effect is larger in emerging markets and developing economies and (iii) for higher levels of financial stress; iv) we deal with simultaneous causality by constructing a novel instrument—financial stress originating from other countries—using information from the text analysis, and show that, while there is clear evidence that financial stress harms economic activities, OLS estimates tend to overestimate the magnitude of this effect; (iv) we confirm the presence of an exogenous effect of financial stress through a difference-in-differences exercise and show that effects are larger for firms that are more financially constrained and less profitable.

Abstract

This paper uses text analysis to construct a continuous financial stress index (FSI) for 110 countries over each quarter during the period 1967-2018. It relies on a computer algorithm along with human expert oversight and is thus easy to update. The new indicator has a larger country and time coverage and higher frequency than similar measures focusing on advanced economies. And it complements existing binary chronologies in that it can assess the severity of financial crises. We use the indicator to assess the impact of financial stress on the economy using both country- and firm-level data. Our main findings are fivefold: i) consistent with existing literature, we show an economically significant and persistent relationship between financial stress and output; ii) the effect is larger in emerging markets and developing economies and (iii) for higher levels of financial stress; iv) we deal with simultaneous causality by constructing a novel instrument—financial stress originating from other countries—using information from the text analysis, and show that, while there is clear evidence that financial stress harms economic activities, OLS estimates tend to overestimate the magnitude of this effect; (iv) we confirm the presence of an exogenous effect of financial stress through a difference-in-differences exercise and show that effects are larger for firms that are more financially constrained and less profitable.

I. Introduction

Financial crises are to economists what earthquakes are to geologists: phenomena of enormous impact about which we have only limited understanding.2 We know what makes them more likely to occur, but we find it extremely difficult to predict their timing and intensity. We design policies to increase resiliency ex ante and emergency response ex post, but we are unable to completely eliminate their devastating consequences. And we are often reminded of the need to develop better forecasting models and policy tools by their sudden reappearance after periods of apparent tranquility. It is therefore no surprise that research about financial crises is often seen as critical in both academia and policy making institutions.

The starting point in understanding the causes and consequences of financial crises is how to define, identify, and measure them. Indeed, while measuring the intensity of an earth tremor is relatively straightforward, evaluating financial stress and defining what counts as a crisis is not. We do not have the economic equivalent of a seismograph. As Romer and Romer (2017) point out, statistical “objective” measures of financial stress, such as credit spreads, may misidentify crisis episodes. They may react to factors other than financial stress (i.e., changes in monetary policy) and may fail to reflect aspects of financial stress episodes (for instance credit rationing) that do not translate into price effects. Further, data on these statistical indicators is typically limited to advanced economies and for relatively short time horizons.

For these reasons, the most broadly used financial-crisis indexes are based on historical analyses of events characterized by major stress in the financial sector combined with statistical indicators. Caprio and Klingebiel (1996) were the first to construct a dataset on bank insolvencies for close to hundred countries. Reinhart and Rogoff (2009) extended the work on banking crisis to 81 countries over the period of 1800 to 2014, and Laeven and Valencia (2013, 2014, and 2020) constructed and later extended one of the most comprehensive financial crises datasets covering 165 countries. All these studies use binary measures to codify financial crises episodes which are admittedly crude as they only capture the occurrence (date) of financial stress but not its intensity (although, Laeven and Valencia also provide more continuous measures such as the fiscal cost of a crisis).

Romer and Romer (2017; RR thereafter) take a different tack on the same approach. First, they confine their historical analysis to the “contemporaneous narrative accounts of country conditions” published semi-annually in the OECD Economic Outlook. This limits the analysis to 24 advanced countries for the period 1967–2012,3 but it allows for more meaningful comparisons across countries and time. Second, they seek to capture variations in crisis intensity and duration and more accurately describe financial stress. In particular, RR extends previous binary measures to an index that “classifies financial stress on a relatively fine scale.” RR demonstrates that, unlike most previous narrative work that sought mainly to identify key crises episodes, it “… may be possible to go further and use narrative sources to code more nuanced developments.” This approach has the potential of capturing financial stress in a more wholistic way including in addition to timing and frequency, also intensity, and duration, all from a single narrative source.

This paper introduces a new index that builds on RR’s approach. We make three important modifications. First, instead of the OECD reports, we rely on the Economist Intelligence Unit (EIU) country reports which allows us to extend the country coverage to 110 countries and the frequency from semi-annual to quarterly over the period 1967–2018. Second, we take a more mechanistic approach at measuring the intensity of financial stress: we rely on search algorithms and word counts in addition to expert judgement. This has two benefits and one cost. On the benefits side: it allows for quick and semi-automatic updating of the series (an important element given the plan is to continuously update the new series); and, by reducing inconsistency as well as errors in human judgment, it further increases cross-country and time-series comparability. On the costs side: it may fail to identify some potentially important information that an expert reader devoted to reading all the relevant reports could exploit to better measure the intensity of financial stress. Our third modification follows suggestions in RR on the desirability to assess more accurately the exogenous contribution of financial stress to declines in output. To this purpose, we carefully examine the narrative in the EIU reports and identify, for each country, episodes of financial stress stemming from financial stress in other countries. Arguably these episodes less driven by domestic economic conditions and could be deemed more exogenous to domestic economic activity.

The new series performs well when put to the test. For OECD countries, our index essentially mimics RR (the correlation is 0.9). Considering the two indexes use different sources and a different approach at measuring intensity, this reassures us that our search algorithm and word count do a more-than-decent job at measuring financial stress. In addition, our measure confirms RR’s findings that financial stress is often building up ahead of the crisis year picked up by most existing binary measures.

In the second part of the paper, we use local projections (Jordà, 2005) to examine the effect of our measure of financial stress on economic activity (GDP and other economic outcomes such as stock market returns, productivity, employment, and uncertainty). We have five main findings. First, consistent with much of the literature, increases in financial stress have detrimental effects on economic activity. In particular, we find that a one-standard deviation increase in our financial stress index is associated with a reduction in the level of output by 0.35 percent one year after the increase in financial stress and by 0.2 percent 5 years after. Second, the extension of the country coverage to emerging markets and developing countries shows quantitative differences in the relationship between financial stress and output across different country groups. The effects of crises tend to be significantly larger for emerging markets and developing economies than for advanced economies. Third, the effect of financial stress on economic activity is non-linear: the effect is small and not statiscally significantly different from zero for lower levels of financial stress, while is large and more precisely estimated for medium-to-high levels of financial stress. This non-linearity is markedly more significant and robust in emerging markets than in advanced economies, adding a qualitative dimension to the quantitative differences reported above. Fourth, using our external financial stress series as an instrumental variable, we show that, while financial stress has a statistically significant exogenous effect on economic activity, simultaneous causality biases OLS coefficients downward—as weaker economic activity tends to intensify financial stress. Finally, we use a large sample of firm-level data covering advanced and emerging economies and a difference-in-differences approach to further strengthen exogeneity and examine firms’ heterogeneity in response to financial stress. The results suggest that increases in financial stress lead to persistent declines in the level of firms’ investment, with the effect being larger for firms that are less profitable (characterized by lower profits, revenues and return on assets) and more financially constrained (characterized by higher debt-to-asset ratios and being smaller and younger).

The remainder of the paper is organized as follows. Section II provides a brief literature review with focus on recent papers aiming to measure financial crises. Section III describes the data sources and methodology used in the construction of the new index. Section IV takes a first look at the index, presenting selected examples of country cases and some notable global trends. Section V empirically examines the effects of FSI on economic activity. The section first reports the empirical strategy used followed by baseline and robustness results. The section ends with an investigation of mechanisms at the macro- and firm-levels. Section VI draws conclusions and poses questions for future research.

II. Literature Review

Existing measures on financial stress fall into two broad strands.4 The first, codifies financial crises with binary variables, and further differentiates them into systemic and non-systemic. Some of the work that fall under this strand include: Bordo et al. (2001), Caprio and Klingebiel (2003), Demirgüç-Kunt and Detragiache (2005), Reinhart and Rogoff (2009), Schularick and Taylor (2012), and Laeven and Valencia (2013, 2014, and 2020).

Bordo et al. (2001) define financial crises as episodes of financial-market volatility marked by significant problems of illiquidity and insolvency among financial-market participants and/or by official intervention to contain those consequences. They identify episodes of financial crises from a review of the historical literature for 56 countries from 1880 to 1998. Caprio and Klingebiel (2003) compile a list of 113 systemic banking crises (defined as much or all of bank capital being exhausted) that have occurred in 93 countries since the late 1970s to 1999. They also provide information on 50 borderline and smaller (non-systemic) banking crises in 44 countries during the late 1970s to 1999 period. Demirgüç-Kunt and Detragiache (2005) use a signals approach and multivariate probability model and their application to studying banking crises in 94 countries from 1980 to 2002.

Reinhart and Rogoff (2009; ReRo thereafter) have compiled a dataset on banking crisis for 81 countries over the period of 1800 to 2014. The construction of the dataset relies heavily on the work of other scholars and they mark a banking crisis by two types of events: (i) bank runs that lead to the closure, merging, or takeover by the public sector of one or more financial institutions, and; (ii) if there are no runs, the closure, merging, takeover, or large-scale government assistance of an important financial institution that marks the start of similar outcomes for other financial institutions. Schularick and Taylor (2012) have assembled a list of financial crises dataset for 14 countries over the period of 1870 to 2008 based on annual coding of financial crisis episodes documented by other scholars. They define financial crises as events during which a country’s banking sector experiences bank runs, sharp increases in default rates accompanied by large losses of capital that result in public intervention, bankruptcy, or forced merger of financial institutions.

Finally, Laeven and Valencia (2020; LV thereafter) have compiled the most comprehensive dataset on systemic banking crises for 165 countries over the period of 1970 to 2017. This effort updates the authors’ global dataset on systemic banking crises (see, Laeven and Valencia 2008, 2013) which has become the gold standard in the literature on banking crises worldwide.5 The dataset is based on defining a banking crisis as an event that meets two conditions: (i) significant signs of financial stress in the banking system; and, (ii) significant banking policy intervention measures in response to significant losses in the banking system. As in Laeven and Valencia (2013), the 2020 update on banking crises episodes is further complemented with dates of sovereign debt and currency crises during the same period. In total, 151 banking crises were identified, in addition to 236 currency crises, and 74 sovereign crises.

The second strand in the literature codifies financial stress with continuous rather than binary variables. Jalil (2015) constructs a series documenting banking panics in the US dating 1825 to 1929. This study uses newspapers as its source of narrative analysis and identifies banking panic episodes which were consequential in periods of output decline. Romer and Romer (2017) in their pioneer work used the narrative approach to develop a more comprehensive series of financial stress chronology using semi-annual data for 24 advanced economies for the period 1967 to 2012.

To construct the new measure, RR use a single, real-time narrative source—OECD Economic Outlook— to classify financial stress on a scale of 0 to 15. To classify financial stress, they start with a keyword search for terms likely to appear in periods of financial stress (e.g., “bank”, “financial”, “crisis”, “rescue”, “bailout”, “crunch”, and “squeeze”) to identify which entries to read more closely. However, from December 2007 volume, they read each volume in its entirety (between 600 – 900 words) as the keyword search returned so many matches. Finally, RR classifies financial stress on a relatively fine scale and further identifies categories of stress to which they assign episodes that have natural interpretations (e.g., credit disruption, moderate crisis, extreme crisis). One of the key contributions in RR is that it convincingly demonstrates how examining narrative sources strengthens the case for a continuous measure compared to a binary measure of financial stress classification.

Another important study in the second strand of the literature is the work by Baron et al. (2021). They use large bank equity crashes to provide an objective, quantitative, and theoretically motivated measure of banking crises. Specifically, they construct a dataset on bank equity prices and dividends for 46 advanced and emerging economies from 1870 to 2016. They supplement existing bank stock indexes with indexes assembled from new, hand-collected stock price and dividend data from historical newspapers. To validate their approach, they show that bank equity prices are strongly correlated with traditional symptoms of banking crises (e.g., likelihood of government interventions to support banking sector, deposit runs, non-performing loans, and bank failures).

In summary, the first strand of the literature is based on annual coding of financial crisis episodes, treats financial crises as a binary variable, and identifies banking crises grounded on narrative information about events such as bank runs and policy interventions. While these binary chronologies cover a large set of countries across long time periods, they have some drawbacks. Discrete chronologies may in general be too coarse. They may miss milder episodes of financial stress or if calibrated to capture these moderate stress events, they are forced to treat them the same way they treat severe episodes.

The second strand in the literature uses continuous measures not only to identify episodes of financial crises but also to characterize their respective intensity. However, this literature so far has covered only a limited set of mostly advanced countries. This paper aims at filling this gap.

There are two important areas where our work contributes to the second strand of the literature. First, our index extends the existing country sample significantly by adding about 80 developing economies and emerging markets and increase the frequency of coverage to quarterly data. Second, we make a deliberate effort to address endogeneity concerns by constructing (from the same narrative analysis) an instrumental variable reflecting stress originating outside a country’s domestic economy to be used in causality identification exercises.

III. Data Collection and Index Construction

This section starts with a brief account of the data source used and the methodology applied to construct FSI.

Data Source

Our sole source for the narrative analysis used to construct our index is the Economist Intelligence Unit (EIU) country reports.6 The EIU, part of The Economist Group, provides insight and analysis of global economic and political developments. As part of its services, the EIU provides country-specific reports covering a large number of countries. Each country report examines and explains the main political and economic developments in the domestic economy. These reports average about 12,000 words in length and are available on a quarterly basis going back to the 1950’s.

To prepare the reports, the EIU relies on a comprehensive network of experts based in the field and in its network of offices in key global hubs. Designated country experts prepare a first draft of the report, based on material from experts in the field, public sources and in-house models, and these are then peer-reviewed, subedited and put through data-quality checks to make the reports consistent and standardized. This rigorous process aims to deliver transparency, accuracy and consistency.

The use of EIU country reports has several advantages. First, they are published with high frequency (minimum quarterly basis), are available over an extended time period (current work covers the period from 1967 to 2018), and cover about 180 advanced, emerging markets, and low-income countries.7 Second, the reports blend data and analytical discussions of country economic developments. Third, the format, topics covered, and level of analysis is relatively consistent both across countries and over time.

On the negative side, one potential shortcoming of any single-source approach is that the resulting index will only be as good as the chosen source (in our case the EIU reports). Put differently, what we gain in tractability and cross-country comparability we may pay in terms of missed information.8 For this reason we see single-source narrative-based indexes as a complement rather than a substitute for the more comprehensive zero-one historical efforts such as LV. That said, we are reassured by the fact that a cross-examination of FSI across other prominent measures in the literature (as discussed later on) shows that our EIU-based measure is fairly consistent with previous series.

Why choose EIU and not an alternative source such as OECD Economic Outlook reports or IMF Article IV reports? We argue that in terms of country coverage, frequency, and reporting consistency, EIU is a solid option. In comparison to OECD reports the clear advantage of EIU is that it covers the large majority of developing economies going back to the 1950’s. With such wide coverage we can get a picture of global financial stress and also focus on emerging markets which as we show in the next section are the recipients of most financial crises and exhibit a relationship between financial stress and economic activity that differs from that in advanced economies. This would not be possible with the OECD reports which cover mostly advanced economies. IMF reports are a very good alternative to EIU and could be considered as the main source for future narrative analysis. For the particular indicator under consideration though, the data variation obtained using quarterly frequency is quite important, and on those grounds, EIU has a clear advantage as IMF Article IV reports are available mostly on annual basis.

Constructing the Index

We construct our financial stress index (FSI) for 110 countries for the period 1967–2018 (we restrict the sample to countries with population above 2 million). Conceptually, we follow Bernanke (1983) and RR and aim at classifying as episodes of financial stress in which an economy experiences an increase in the cost of credit intermediation or disruptions to the credit supply. As described by RR, the rise in cost of credit intermediation includes both a higher cost of funds for financial institutions relative to a safe interest rate and an increase in other operational costs associated with their lending activities. Put differently, we want to identify episodes in which, for a given level of the expected return on safe assets, the cost (quantity) of credit to the economy increases (decreases). Note that this definition excludes reductions in the supply of credit stemming from increases in interest rates due “normal” cyclical factors such as tighter monetary policy.

We follow a four-step process to construct the index. First, similar to RR, we search the EIU reports for words likely to be associated with descriptions of financial stress. More specifically, we identify paragraphs/lines containing two set of keywords: (i) credit, financial, bank, lending, and fund, and; (ii) crisis, crunch, squeeze, bailout, rescue, tight, contract, and reluctant.

In the second step, we read the paragraphs extracted in step 1 to confirm that the text is indeed describing developments associated with contemporaneous financial stress. The point here is to exclude false positives. An example classified as financial stress related to domestic event is the following: United States (2009Q4): “The administration will also continue to focus on supporting a recovery from the financial and economic crisis and to implement measures that help to avoid a recurrence of such a crisis.” To determine whether recovery from a crisis is a signal or noise of contemporaneous financial stress, we focus on whether the economy is “under the process of recovery” or “fully recovered from the financial stress”. In this case, we read that the government is “supporting a recovery”, which indicates that US is still recovering, and the effects of crisis still exist. There is no mention of the stress originating from external causes, therefore, by default, we take “crisis” here as a signal of domestically originated financial stress. At this stage, we also look for text that refers to an increase in the cost of credit intermediation due to developments external to the country (e.g., financial crisis in country A spreading to country B and leads to financial stress in country B). An example classified as financial stress related to external shock is the following: Denmark (2008Q2): “In response to the global credit crunch, the national bank has opened a new seven-day secured lending facility to support liquidity in the money market.”

Our search algorithm picks several false positives. For instance, Colombia (2000Q3): “The financial services sector, having contracted by some 10% in 1998–99, continues to consolidate by cutting costs, capitalization and rebuilding reserves.” We do not count this event as a contemporaneous financial stress episode. The text does not mention financial stress—that is, the contraction could be simply due to a correction in a previous expansion of the sector—nor the sources causing the contraction in financial services sector, and it refers to events one-to-two years before the publication of the report. This and other examples show how crucially important was to the data construction process the reading and validation of the text by an expert. We calculated that the text search procedure used produced over 50 percent false positive signals which had to be manually evaluated and eliminated by human judgement. It is estimated that about half of the substantive work done in the data construction work involved carefully reading of text and validation by a human expert.9

In the third step, we asked IMF country economists to cross-validate the identified signals, resulting in the correction of the index for few cases (such as Ecuador, Nepal, and Venezuela).

In the last step, we sum the verified signals of financial stress in each period. An obvious difficulty with these raw counts is that the overall length of country reports varies across time, and across countries. Thus, to make the index comparable across countries, we scale the raw counts by the total number of words in each report.10 Two factors further help improve the comparability of the index across countries. First, the index is based on a single source. Second, the reports follow a standardized process and structure. In addition, the process to put together the reports described earlier helps to mitigate concerns about the accuracy, ideological bias and consistency of the index.

IV. Financial Stress Index (FSI): Global Trends and Country Experiences

Next, we report global, regional, and country-specific financial stress trends and episodes using our newly constructed index. Also, for validation, we compare our index with existing chronologies.

Global Movement

Figure 1 shows that global financial stress as measured by the FSI rose during the Latin America debt crisis in the 1980s (often known as “La Década Perdida,“ The Lost Decade), the Mexican Peso Crisis in the mid-1990s, the financial crisis in Asia, Russia, and Latin America (also coinciding with the Long-Term Capital Management episode) in the late 1990s, and then rose sharply during the Global Financial Crisis (GFC) and Europe’s sovereign debt crisis between 2008–2013. The index then remained relatively stable at least until our last observation in 2018 (an update to current times would likely show some activity during the COVID crisis).

Heterogeneity across Country Income Groups

The magnitude of financial stress varies significantly across income and regional country groups and also across events. Figure 2 shows significant heterogeneity in stress levels across advanced, emerging and low-income economies. For instance, in 2008Q4, the level of the FSI is close to the global average in emerging economies, below it in low-income economies, and about three times it in advanced economies. This is in line with the GFC been described as a crisis of advanced economies.

Averages vs. Episodes

The average level of financial stress over the 1967–2018 period is higher in advanced economies than in emerging economies. Panel A in Figure 3 shows that on average the level of financial stress is 0.033 in advanced economies, followed by 0.025 in emerging economies, and 0.010 in low-income economies. However, the picture changes if we look deeper into the data. If we exclude the period 2008 to 2012 (GFC), the average level of FSI is higher in emerging economies, followed by advanced economies, and low-income economies (Figure 3, Panel B). Moreover, Figure 3c shows that the number of -quarters with financial stress (normalized by number of countries) is highest in emerging economies (20.7 quarters), followed by advanced economies (15.7 quarters), and low-income economies (13.7 quarters). The low FSI values for low-income economies in all three panels in Figure 3, likely reflect less developed and interconnected financial sectors--a leading explanation as to why these economies survived the GFC better than richer countries.

Regional Heterogeneity

Finally, Figure 4 shows the level FSI across geographical regions. It shows little financial stress in Africa and the Middle-East and Central-Asia—regions characterized by lower levels of income per capita and financial development. In contrast, the Asia-Pacific region shows financial stress during the Asian crisis as well as during the GFC. In the Western Hemisphere, the FSI registers elevated levels during the financial crises in the region in early 1980s, late 1990s and during the GFC. And, for Europe, the FSI captures financial stress during GFC and the European sovereign debt crisis.

Comparison of FSI with Existing Chronologies

Next, we focus on how our new FSI compares with existing measures of financial stress/crises. Table

I reports key characteristics of our measure and those by RR, ReRo, and LV.11 It shows that the country coverage, frequency, and time coverage varies across measures and that FSI generally compares favorably to other measures along all three dimensions. Table 2 provide simple pairwise correlations between each of the four measures. The correlation between FSI and RR in the overlap of observations available to both indices is remarkably high at 0.9 despite the different sources and different approaches at evaluating stress intensity. Similarly, the correlations between the FSI and the two binary indicators are also high—at 0.4 with LV and 0.4 with ReRo—but lower than with respect to RR, likely reflecting the fact that our FSI is positive for many zeros recorded in the binary chronologies. And third, the correlation between any two indicators from RR, RoRe, and LV, is in the range of 0.5 to 0.7.

To highlight commonalities and differences across measures, Figure 5 compares FSI with the other three selected existing measures of financial stress for a set of 8 countries: the United States, South Korea, Honduras, Argentina, the Philippines, Nigeria, Costa Rica, and Rwanda.12 Data for LV ends in 2017, for ReRo ends in 2014, and RR ends in 2012, so in Figure 5 we restrict our data to match these sample periods. Using these country cases, we can make four noteworthy observations. First, as seen in the case of the US (Panel A) our measure is very closely aligned with that of RR. This is indeed the experience in most of the countries for which there is data overlap in the two indices. Compared to the LV and ReRo binary indicators, our indicator, as that of RR, captures the severity of the stress more accurately—for instance, the binary indicators are unable to distinguish between the severity of the Savings and Loans crisis against that of the GFC.

Second, the broader country coverage of FSI relative to existing continuous stress measures, allows for a greater examination of heterogeneity in the severity and duration of financial stress across countries and episodes. For example, Panels B, C, and D report comparisons of the three chronologies for Argentina, Philippines and Nigeria, respectively—countries not covered by RR. It is clear in all three cases that while the FSI is in broad agreement with LV and ReRo on the timing of financial stress, there exist glaring differences in intensity across these episodes. Take the Argentina case (Panel B): all three indices capture the timing of the Latin America Debt Crisis in the 1980s, the Mexican Peso crisis of the 1990’s, and the most severe Argentina crisis of 2001. However, the binary indicators fail to capture differences in severity across these crises, thereby equating what seems to have been a mild financial stress period during the Mexican Peso crisis to the severe Argentine financial crisis of 2001.

Third, there are some cases in which intensity measures do not capture any financial stress episodes, while binary chronologies do, and vice versa. For instance, in the case of Honduras (Panel E) FSI identifies a long period of severe financial stress (1980–1985) related to the broader debt crises in Latin America,13 while the two binary measures do not pick up any financial stress. And conversely, in the case on Korea (Panel F), ReRo identifies a period from 1985 to 1989 of financial stress that is not identified by FSI. One possible explanation for these two differences is that the definition of financial stress to construct FSI and the definition of banking crisis in ReRo and LV are not identical. In the case of Honduras, we identified narratives such as “liquidity crisis”, “credit squeeze” and “financial crisis” from 1980 to 1985, which are clear signs of financial stress to construct the FSI. But neither ReRo nor LV identified such period. In LV’s study, two conditions should be met to identify a banking crisis: 1) significant signs of financial stress in the banking system; and 2) significant banking policy intervention measures. In EIU reports, we do not observe any policy intervention, which indicates that the first condition is met, but the second condition is not met—and that could possibly explain why such period is not identified as banking crisis in LV’s study. In the case of Korea, the difference in the definition also seems to play a role. ReRo has a rather broad definition of financial stress (banking crisis) compared to the definition of FSI. The large-scale financial liberalization in Korea in the 1980s, and the subsequent increase in the number of banks, is seen as a risk of a banking crisis (Reinhart, 2002; Shin and Hahm, 1998). This case would be barely picked up by our index because we follow a stricter definition of financial stress, which captures a shortage of credit supply. In contrast, in Korea in the 1980s, the credit supply was increasing steadily. This is consistent with the data from LV, whose study finds no systemic banking crisis in mid 1980s, because it follows a rather strict standard to identify systemic banking crisis.

Fourth, in a few country cases, FSI and the binary chronologies simply do not match in identifying financial stress. Panels G and H report such instances for Costa Rica and Rwanda, respectively. For the case of Costa Rica, FSI moves only very little during the 1987 and 1995 crises identified by both LV and RoRe. This case could also be due to the differences in the definition of the measures of financial stress. According to ReRo and LV, the first period of banking crisis from 1987 is identified due to extremely high levels of non-performing loans in the banking system; and the second crisis is led by the closure of the third largest bank in the country. The narratives in the EIU reports of Costa Rica during these two periods, barely mention signals that we use to pick up financial stress. In contrast, FSI spikes in 1967 as the EIU explicitly mentions “economic and financial crisis that now seems endemic in Costa Rica”, while ReRo and LV identifies this as debt and currency/external crisis. For Rwanda, FSI identifies two periods of stress that are not identified by LV. From the EIU reports, FSI picks up narratives such as “tight liquidity” in 1985 and “liquidity squeeze” in 2009, which are signals for financial stress. In 1985, “strained treasury and corporate bond is draining liquidity in the banking sector”, which causes financial stress. In 2009, the financial stress is due to withdrawals of funds by major depositors, losses on foreign investments, and lower domestic saving, which is possibly associated with the Global Financial Crisis.

Overall, these discrepancies suggest that these measures are complements rather than substitutes, with costs and benefits on both sides. More generally, while we hope to have demonstrated that our new FSI has a high signal-to-noise ratio in identifying financial stress episodes and overall compares favorably with existing narrative measures, we recognize that it is by no means always the preferred one.

Finally, the FSI is also positively and statistically significantly correlated with statistical measures of financial stress such as the Financial Condition Indices (FCIs) developed by the IMF (2017)— correlation about 0.45—suggesting that the index could also be used as complement to these statistical indicators when they are not available.14

V. Empirical Analysis: The Effect of FSI on Economic Activity

In this section, we investigate the economic effect of financial stress using country- and firm-level data.

Using country-level information, we proceed in two steps. First, we use the quarterly frequency of the data to estimate the baseline effects of our financial stress indicator on GDP for a panel of 49 countries for which data is available, consider nonlinearities in the relationship between the severity of our index and GDP, and how it varies across country groups—Advanced Economies (AEs) vs. Emerging Market and Developing economies (EMDEs). In a second step, we subject our baseline results to a battery of robustness tests.

These includes alternative data samples, alternative specifications, and alternative data frequencies— in particular, we use annual data which allows us to increase the county and time dimension of our sample but also to compare the estimates from FSI with those from previous measures. Finally, we construct a novel instrumental variable which we use to deal with simultaneous causality. This is a key contribution of this paper to the existing literature as it provides an identification strategy that does not rely on sectoral data and a diff-in-diff approach and hence allows for an estimation of level effects.

Next, we extend the analysis by using a comprehensive quarterly firm-level dataset for a set of sixty-three AEs and EMDEs over 20 years. This extension makes two important contributions. First, the large coverage of the dataset (over 20,000 firms in our sample) along with the extensive firm heterogeneity makes it possible to estimate the economic effects of financial stress with much more precision than when using country-level data.

Second, and more important, it complements our IV approach in dealing with simultaneous causality. As in previous studies (see for instance, Dell’Ariccia et al., 2008; and Kroszner et al., 2007) we employ a difference-in-differences framework—assigning firms into different groups based on their exposure to external finance—which includes country-sector-time fixed effects. The working assumption is that financial stress should have a greater impact on firms that rely more on external finance, while fixed effects effectively control for domestic macro-economic shocks (such as the policy response in the domestic economy). Evidence of a differential effect across firms, would thereby confirm the presence of causal effect from financial stress to economic activity.

Country-level Analysis

Empirical Methodology

To examine the dynamics of output following changes in financial stress, we follow the local projection method proposed by Jordà (2005), a methodology used also by Auerbach and Gorodnichenko (2013), RR, and Alesina et al. (2019) among others. This procedure does not impose the dynamic restrictions embedded in vector autoregression specifications and is particularly suited to estimating nonlinearities in the dynamic response. The first regression we estimate is:

yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk,(1)

where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects included to take into account differences in countries’ average economic performance; γt are time fixed effects, included to control for economic developments facing all countries in a given year; ΔF denotes the change in financial stress.

In the baseline, we estimate Equation (1) for an unbalanced sample of 49 countries for which we have quarterly data from 1996Q1 to 2018Q4. Limited availability for quarterly data dictates the boundaries of this sample. As a robustness check and extension, we investigate the sensitivity of our results to a larger sample of 110 countries, using annual data from 1967 to 2018.

Equation (1) is estimated using ordinary least squares (OLS) for horizon (quarter) k = 0,…,20. The coefficient βk denotes the “impact” of changes in FSI on output at a given horizon k. Impulse response functions are computed using the estimated coefficients βk, and the confidence bands associated with the estimated impulse-response functions are obtained using the estimated standard errors—clustered at the country level—of the coefficients βk.

In the baseline, we do not take a stance on the drivers of financial stress—that is, we do not distinguish between changes in financial stress stemming from other countries and that can therefore be considered “more exogenous” to domestic economic activity, from endogenous ones that arise from domestic conditions. Later on, we investigate the sensitivity of our results to exogenous changes in financial stress, either using these foreign-originated changes as an instrument for overall changes in financial stress or directly as regressors.

Data Sources

The quarterly and annual macroeconomic series for GDP, employment, labor productivity (defined as the ratio of GDP to employment), unemployment, policy rates and cyclically adjusted balance are taken from the IMF World Economic Outlook. The classification of countries in income groups (advanced vs. emerging markets and developing economies) and regions (Africa, Asia-Pacific, Europe, Middle-East and North Africa (MENA) and Americas) follows that of the IMF World Economic Outlook. Data for uncertainty are taken from Ahir, Bloom and Furceri (2022). Data on stock returns and return volatility are taken from Baker, Bloom and Terry (2021).

Baseline Results

Table 3 presents the results obtained estimating Equation (1) for each horizon (quarter) k, from 0 to 20. The lagged output coefficient, as expected, is close to 1, suggesting that the level of GDP is non-stationary and that the country fixed effects capture average GDP growth rates.15 The country fixed effects are jointly statistically significant, as are the time fixed effects, reflecting the importance of global shocks.

Figure 6 presents the evolution of (log) output following a one-standard deviation increase in FSI (this is equivalent to 0.1 changes in the index). Time is indicated on the x-axis; the solid line displays the average estimated response, shaded areas denote 90 percent confidence bands. The results suggest increases in financial stress are associated with sizeable and persistent reductions in the level of output, and transitory ones in the growth rate of the economy. In particular, we find that a one standard deviation increase in FSI (such as that experienced by Germany in the third quarter of 2011) is associated with a reduction in the level of output by 0.35 percent one year after the increase in financial stress and by 0.2 percent 5 years after. This result is highly statistically significant, economically sizeable, and appears reasonable.

To put it in perspective, the results suggest that the peak increase in financial stress observed in the United States during the GFC (1.7 in the fourth quarter of 2018) would have been associated with a reduction in US GDP by about 6 percent in 2019—an estimate in line with the range found in the literature (e.g., RR).

Heterogeneity: Advanced vs. Developing Economies

Several studies using binary chronologies of crises suggest that the economic effects of banking crises tend to be larger in EMDEs than in AEs (see e.g., Cerra and Saxena 2008; Gourinchas and Obstfeld 2012; and Claessens et al. 2009, 2014). To corroborate this evidence, we re-estimate the following equation:

yi,t+k=αik+γtk+β0kAEDΔFi,t+β0kEMDE(1D)ΔFi,tjΣj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk,(2)

where D is a dummy variable which takes value 1 for AEs, and zero otherwise. The coefficients βkAE and βkEMDE capture the relationship between output and financial stress for AEs and EMDEs, respectively.

The results reported in Figure 7 show that the response of GDP to an equal increase in financial stress, is more than twice larger in EMDEs than in AEs. This result is consistent with some existing literature based on the binary indicators which points to the greater economic severity of financial crises in EMs. However, the novelty of our results is that, thanks to the FSI intensity dimension, we are able to highlight that what drives the heterogeneity in the output response across AEs vs EMDEs is not the different severity of financial stress (since we are comparing the responses to the same increase in financial stress) but rather the differences in economic resilience, including the ability and space of fiscal and monetary policies to respond to financial stress.

Nonlinearities: Severity of Financial Stress

To investigate the possibility that more severe stress levels are disproportionately more detrimental to output than moderate levels, we estimate variants of our baseline specification that relax the assumption that the relationship between output and financial stress is independent of the level of financial stress. In particular, we modify Equation (1) as follows:

yi,t+k=αik+γtk+β0kGI[FitG]ΔFi,tΣj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk,(3)

where I is an indicator function which assumes value 1 when the level of financial stress belongs to a specific bin (terciles) of the distribution, which we refer to as group G. The coefficients β0kG capture the relationship between output and financial stress at horizon k for each “group” of financial stress. The main benefit of this specification is that it does not impose any functional form to capture non-linearity in the way the effect of financial stress on output varies across groups (low, medium and high) of financial stress.

The estimates reported in Figure 8 Panel A suggests nonlinearities in the response of the economy to financial stress: the effect of financial stress on output is small and not statically significantly different from zero for lower levels of financial stress, while is precisely estimated and larger than the baseline estimates of Figure 6 for medium-to-high levels of financial stress. The differences in the response between low vs. medium financial stress and low vs. high financial stress are statistically significant up to k=11. However, they become insignificant in the medium-term because of the large confidence bands associated with the medium-term point estimates for the low-financial stress regime (Table A4). Overall, these results are consistent with Baron et al. (2021), that find non-linear effects of bank equity returns on output and bank credit.

Next, we examine whether the extent of non-linearity in the relation between financial stress and output vary between AEs and EMDEs. To do so, we estimate a variant of Equation (3):

yi,t+k=αik+γtk+β0kGAEI[FitG]ΔFi,t+0kGEMDEI[FitG](1D)ΔFi,t+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk.(4)

The results reported in Figure A2 show that for both group of countries, the output responses are not statistically significant for low levels of financial stress but become larger and more precisely estimated for medium-to-high levels of financial stress. Notably, the non-linearity is more pronounced and significant in EMDEs than AEs (where it is significant only at high levels of stress).

These results are robust to alternative specifications to capture non-linearity in the relation between financial stress and output. As a first alternative, we consider a variation of equation (2) in which D takes value 1 if the level of financial stress is above the median of the distribution, and zero otherwise. In a second alternative specification, we replace D with a smooth transition function of the level of financial stress. The results reported in Figure A2 confirm non-linearity: the response of the economy following an increase of a given size in financial stress is large and statistically significantly when the initial level of stress is already high, while being small and typically not statistically significant when the level of financial stress is initially low.16

Robustness Checks

To check the robustness of these results, we performed several sensitivity tests across alternative samples and specifications.

Alternative samples. We considered samples dropping the following sets of observations: a) Outliers (those observations corresponding to the residuals in the output regression in the bottom and top percentiles of the distribution); b) High inflation episodes (inflation above 20 percent); c) Observations from the Americas; d) Asian and Sub-Saharan African economies; e) Drop small countries; f) Episodes of large changes in financial stress episodes (those corresponding to the 99th percentile of the distribution); g) Observations pertaining to the period following the GFC (after the third quarter of 2008).17 The results are shown to be robust to all these perturbations as reported in Figure 9.

Alternative specifications and control variables. We considered two main modifications to Equation (1). First, we restrict the change in the financial stress indicator to enter Equation (1) only with a lag—that is, we do not estimate the contemporaneous effect of financial stress on GDP. This is equivalent to estimate, for k>1, the GDP effect of changes in financial stress that are orthogonal to contemporaneous changes in economic activity. Second, we add a set of control variables that may be related to financial stress and affect output—such as changes in monetary policy rates, changes in cyclically adjusted budget balance, stock market growth and volatility, and economic uncertainty. The results reported in Figure 10 are not statistically different from those reported in the baseline.

Alternative data frequency. We also re-estimate Equation (1) using annual data for an unbalanced panel of 110 countries over the period 1950–2018. Table 4 presents the results obtained for each horizon (quarter) k, from 0 to 5, and Panel A in Figure 11 presents the evolution of (log) output following a one-standard deviation increase in the financial stress indicator (this is equivalent to 0.1 changes in the index). The results confirm that increases in financial stress are associated with sizeable and persistent reductions in on the level of output, and transitory ones in the growth rate of the economy. In particular, we find that a one-standard deviation increase in the financial stress indicator is associated with a reduction in the level of output by 0.8 percent one year after the increase in financial stress and by 0.6 percent 5 years after. This estimate is highly statistically significant, and even larger than the one obtained using quarterly data. To check whether this larger estimate is the result of a larger sample, we repeated the analysis constraining the sample to be the same as the one used for the quarterly data. The results confirm the larger estimate obtained using annual data (Figure 11 Panel B). A possibility for this larger estimate is that reverse causality tends to be larger using annual data. This suggests that analysis on the effect of financial crises and stress using annual data are likely to overestimate the macroeconomic effect of financial stress.

Comparison with other Chronologies

Next, we compare the relationship between FSI and output using annual frequency (to allow comparisons across all measures) to those obtained using other measures. To do so, we re-estimate Equation (1) using the measures of: (i) RR (annualized); (ii) LV; and (iii) ReRo—aiming at maximizing the overlap of the estimation sample as well as the number of episodes of financial stress. We report the results in Figure 12. For each alternative measure, we report their output response as well as the output responses obtained using our index over the same sample. In particular, in the left panels we report the estimates for FSI over the samples for which RR, LV and ReRo are available. In the right panels, we show the responses of the financial stress together with the other chronologies.

The results point to two main findings. First, the responses reported in the left panels confirm the robustness of the estimates for FSI over alternative samples. Second, the magnitude of the estimates varies across chronologies. While the output effects of a one standard deviation increase in our index are in the same ballpark than that those associated with a of a one standard deviation increase in RR index, they are about one-tenth smaller than those associated with the financial crises identified in LV and ReRo.

This result provides strong support for the evidence reported previously suggesting that the relationship between financial stress and economic activity is non-linear and steepens with the intensity of the financial stress—a dimension binary measures do not capture.

Addressing Endogeneity

To address endogeneity concerns, we carefully examine the narrative in the EIU reports describing the episodes of financial stress and identify those stemming from financial stress originating outside each country.18 Arguably these episodes are less driven by domestic economic conditions and can be treated as exogenous to GDP. Indeed, estimates of these changes on their own lags and contemporaneous and lagged GDP confirm that this is the case (Table 5).

Once these episodes are identified we use them as instruments for the overall changes in FSI. In particular, our IV strategy reads as:

yi,t+k=αik+γtk+β0kΔFi,t^+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk

and

ΔFi,t=πi+τt+ϑΔEFi,t+Σj=12ρjkΔFi,tj+Σj=02σjkyi,tj+μt,(5)

where EFi,t is the indicator of external financial stress. The first stage estimates suggest that the instrument is “strong” and statistically significant. The Kleibergen–Paap rk Wald F statistic—which is equivalent to the F-effective statistic for non-homoskedastic errors in case of one endogenous variable and one instrument (Andrews et al., 2019)—is about 1200, about 75 times the associated Stock-Yogo critical value (16.38).

Our IV results support the findings obtained with OLS: the baseline IV result indicates a significant negative and persistent effect of financial stress (Figure 13). However, the magnitude of the IV coefficient estimates is smaller in absolute value than the OLS estimate, which suggests that OLS estimates are downward biased and should be considered an upper bound of the negative effect of financial stress on economic activity. This is consistent with the evidence that some financial stress is a consequence of declines in economic activity.

To test the validity of our instruments, we run several checks. First, we test whether the instruments have a direct effect on economic activity by including them as additional controls in the baseline model (Table 6). If the coefficients turned out to be negative and significant, one could argue that the instrument is part of the error term and thus does not satisfy the exclusion restriction. The results suggest that this is not the case. Second, we test directly the association of the baseline residuals and the instrument. The results suggest that the relationship is indistinguishable from zero (Table 7), which supports the validity of our instruments.

Additionally, we exclude from the analysis, once at the time, the United States and other G7 economies as domestic economic conditions in these larger economies are more likely to generate financial spillovers in other countries, which could then spill back home. Also in this case, the results confirm the validity of our instruments (Figure 14). We also consider the possibility that external financial stress transmits not only through the financial channel (therefore, leading to an increase in financial stress in the domestic economy) but also through trade. To control for this possibility, we expand the regression to include GDP growth in major trading partners. Also in this case, the results corroborate the validity of our instruments (Figure 15). In addition, we also re-estimate Equation (1) using external financial stress directly as main regressor, instead of as instrument for overall financial stress. The results are qualitatively unchanged.19

Finally, we re-estimate Equation (2) using annual data and also re-estimate Equation (2) and (3) with an IV approach (see Figure 1618). Similarly, to what was found above, the results, although smaller in magnitude, are qualitatively consistent with the OLS results.

Channels

We finish the cross-country analysis by making a first attempt at exploring channels through which financial stress may affect output. We do so by re-estimating Equation (1) using potential drivers of output as alternative dependent variables as follows: (i) labor productivity; (ii) employment; (iii) unemployment; (iv) the growth rate of stock market returns; (v) stock market volatility; and (vii) economic and policy uncertainty (World Uncertainty Index by Ahir, Bloom and Furceri, 2022). The results reported in Figure 19 suggest that a key channel is the statistically and economically significant decrease in labor productivity, which declines by about 2 percent after one year following a one-standard deviation increase in financial stress. Increases in financial stress have also negative effects in the labor market by reducing employment about 1 year after the shock and increase the unemployment rate by about 0.1 percentage point, 1 year after the shock. Finally, the results corroborate existing evidence that increase in financial stress is associated with a short-term decline in stock market growth, and short-lived increase in stock market volatility and uncertainty (e.g., Caggiano et al., 2021 and references therein). Similar results are obtained when using the IV approach (Figure 20).

Firm-level Analysis

In this section, we complement our cross-country analysis with firm-level analysis. Taking advantage of extensive firm coverage and heterogeneity helps with identification and allows for further testing causality through a difference-in-differences approach.

Data

Our main source is S&P Capital IQ (CIQ), which provides extensive firm balance sheet and income statement information. The main advantage of this dataset compared to other leading corporate data providers such as Orbis or Worldscope is that data are available at the quarterly frequency, which is more suited to identify the firm-level responses to high frequency shocks—such as financial stress episodes.

The dataset covers 150 countries from 1950Q1 to 2021Q2. In order to reduce significant gaps in the time series, we restrict the sample to 2001Q1 onwards, and to 75 advanced and emerging market economies. Details regarding the sample of countries used in the analysis, by geographic region, are available in Table A6. The data is restricted to non-financial corporations and was cleaned to remove firms which had negative values for assets or debt in any year, and observations with the incorrect sign for revenue, capital expenditure, cash, tangible assets, and interest expenditure were set to missing—see Kim et al. (2020) and Arbatli-Saxegaard et al. (2022) for details. We further restrict the sample to exclude real estate and insurance companies. Tables A7 and A8 display the number of firms across countries and 20 economic sectors.

We make use of a set of balance sheet and cash-flow statement indicators from S&P Capital IQ to investigate the response of firm-level investment to financial stress, and its heterogeneity depending on firms’ characteristics. As for our investment measure, we use capital expenditures (IQ_CAPEX-2021). This variable refers to funds used by firms to acquire assets—such as property, plant, or equipment—and generally used to undertake new investments.

Empirical Methodology

Our empirical approach to quantify the effect of financial stress at the firm-level proceeds in two steps. In the first step, we estimate the average (unconditional) effect of financial stress on firm investment using Jordà’s (2005) local projections. Specifically, we estimate the following specification:

yn,i,t+k=αisqk+γnk+Σj=12βjkΔFi,tj+Σj=02θjkyn,i,tj+εn,i,tk,(6)

where dependent variable, yn,i,t+k, is the investment ratio in firm n of country t at time (quarter) t; ΔFi,t denotes the change in the financial stress indicator at time t; γn indicate firm fixed effects to control for unobservable time-unvarying firm characteristics and αisqk are country-sector-quarters dummies to account for cross-sector variations across countries as well as seasonality in the data.

In the second step, we expand equation (6), to estimate how the effect of financial stress varies across firms. We apply a difference-in-differences approach based on the identifying assumption that financial stress has larger effects on firms that are less profitable (characterized by lower profits, revenues and ROA) and that are more financially constrained (characterized by higher debt-to-asset ratios and being smaller and younger). In particular, we estimate the following specification:

yn,i,t+k=αisqk+γnqk+Σj=k4μjkΔFi,tj*Dn+Σj=14θjkyn,i,tj+εn,i,tk,(7)

where D is a dummy which equals to one if the with the firm country characteristics is below (above) the median of the country.20 We use the average profitability over the entire sample to define this dummy to reduce endogeneity due to the potential time-varying response of corporate debt to recessions. αistk are country-sector-time fixed effects to account for macro-economic shocks and their differential effect across sectors (such as the differential effect of financial stress) as well as sector-specific shocks at the country level (such as changes in country regulations affecting a given sector). γnqk are firms-quarter dummy to account for firms’ characteristics as well as seasonality in the data.μjk indicates the marginal (additional) response of investment to financial stress in quarter k for firms with a low (below-median) level of profitability relative to those with high levels of profitability. Equations (4)-(5) are estimated using OLS (and IV) and standard errors are two-way clustered on firm and country-time.

Results

Figure 21 presents the response of (log) investment to an increase in financial stress. Time (quarter) is indicated on the x-axis; the solid line displays the average estimated response, dashed and dotted areas denote 90 and 68 percent confidence bands, respectively. The results suggest increases in financial stress are associated with persistent effects on the level of investment. In particular, we find that a one-standard deviation increase in financial stress is associated with an average reduction in the level of firms’ investment of about 30 percent after 12 quarters. This effect is statistically significant and economically sizeable.

Figure 22 reports the differential response of investment to financial stress between a firm with relatively low profitability/high financial constraints and firms with relatively high profitability/low financial constraints. The results show that the differential investment loss for a firm with low profitability/high financial constraint is statistically significant and precisely estimated across all variables and most of the horizon considered, with the peak effect being economically sizeable at about 10 percent. These results are robust when estimating Equation (7) with the IV approach using the external financial stress indicator as the instrument (Figure 23).

VI. Conclusions

This paper uses text analysis to construct a continuous financial stress index (FSI) for 110 countries quarterly over the period 1967–2018. The new indicator has a larger country and time coverage and higher frequency than similar measures focusing on advanced economies (RR) and it complements binary indicators with broad country coverage extended the work on banking crisis to 81 countries over the period of 1800 to 2014 (Laeven and Valencia 2013, 2014, and 2020; and Reinhart and Rogoff, 2009) by providing a continuous measure of financial stress intensity. Further, since FSI relies primarily on a computer algorithm, it is easy to maintain and update.

We use our new indicator to revisit a set of key questions in the literature: What is the effect of financial stress on output? Can we establish a causal effect between financial stress and output loss? Is this loss temporary or persistent? Does the severity of financial stress affect its relationship with output? And is the relationship different in advanced economies, emerging markets, and developing countries?

We confirm the existence of an economically significant and persistent relationship between financial stress and output. Further, using our newly constructed series of “foreign-originated” stress we provide evidence of a causal effect of financial stress on output, but also suggest that OLS estimates will tend to overestimate such effect. Our IV approach contributes to the literature by providing novel “simultaneous-causality-proof” level estimates of the effect. Yet, we also use firm-level and a diff-in-diff approach to further confirm the direction of causality in the relationship between financial stress and economic activity.

We exploit the broad country coverage and continuous nature of our index to explore the crosscountry heterogeneity of the relationship between financial stress and output. We confirm evidence that crises tend to be more disruptive in EMDCs than in AEs. But we also show that this is not due solely to the fact that less advanced economies are exposed to larger shocks. Rather, even for comparable levels of financial stress, the effects on output tend to be larger in EMDCs, suggesting that greater fiscal and monetary policy space and stronger institutional frameworks are likely to play a role. Finally, especially for EMDEs, we find evidence of nonlinearities in the relationship between financial stress and economic activity, with the effect being typically not significant for low levels of financial stress.

This paper opens important questions for future research. First, across all 110 covered countries, we observe that generally FSI tend to pick up the start date of stress earlier than the binary measures and this is especially true for developing economies. Future research could investigate whether and under what conditions an early rise in FSI could serve as a warning indicator for more severe financial crises. Second, what are the mechanisms through which financial stress impacts output? Our initial attempt points to labor productivity and unemployment as promising areas of future research. Second, further work using text analysis would certainly contribute to the frequency of observations and depth of the narrative around each observation. Third, extending the empirical exercises in this paper using emerging sources of firm-level data across different sectors and countries seems also an exciting venue of research.

References

  • Adrian, Tobias, Fernando Duarte and Tara Iyer. 2023, “DP17777 The Market Price of Risk and Macro-Financial Dynamics”, CEPR Press Discussion Paper No. 17777.

    • Search Google Scholar
    • Export Citation
  • Adrian, Tobias, Federico Grinberg, Nellie Liang, Sheheryar Malik, and Jie Yu. 2022. “The term structure of growth-at-risk.” American Economic Journal: Macroeconomics 14, no. 3: 283323.

    • Search Google Scholar
    • Export Citation
  • Ahir, Hites, Nicholas Bloom, and Davide Furceri, 2022, “World Uncertainty Index,” NBER WP 29763.

  • Alesina, Alberto, Carlo Favero, and Francesco Giavazzi. 2019. Austerity: When It Works and When It Doesn’t. Princeton, NJ: Princeton University Press.

    • Search Google Scholar
    • Export Citation
  • Andrews, Isaiah, James H. Stock, and Liyang Sun. 2019. “Weak Instruments in Instrumental Variable Regressions: Theory and Practice,” Annual Reviews, 11, 727753.

    • Search Google Scholar
    • Export Citation
  • Arbatli Saxegaard, Elif, Davide Furceri, Jeanne Verrier, and Melih First. 2022. “U.S. Monetary Policy Shock Spillovers: Evidence from Firm-Level Data,” IMF WP 2022/191.

    • Search Google Scholar
    • Export Citation
  • Auerbach, Alan J., and Yuriy Gorodnichenko. 2013. “Output Spillovers from Fiscal Policy,” American Economic Review, 103 (3), 141146.

    • Search Google Scholar
    • Export Citation
  • Baker, Scott, Nick Bloom, and Stephen Terry. 2021. “Using Disasters to Estimate the Impact of Uncertainty,” Review of Economic Studies (forthcoming).

    • Search Google Scholar
    • Export Citation
  • Baron, Matthew, Emil Verner, and Wei Xiong. 2021. “Banking Crisis without Panics,” Quarterly Journal of Economics, 136 (1), 51113.

    • Search Google Scholar
    • Export Citation
  • Blanchard, Olivier, Giovanni Dell’Ariccia, and Paolo Mauro. 2010. “Rethinking Macroeconomic Policy,” Journal of Money, Credit and Banking, 42, 199215.

    • Search Google Scholar
    • Export Citation
  • Blanchard, Olivier, Giovanni Dell’Ariccia and Paolo Mauro. 2013. “Rethinking Macroeconomic Policy II: Getting Granular,” IMF Staff Discussion Note, 2013/03.

    • Search Google Scholar
    • Export Citation
  • Bloom, Nicholas, Scott Baker, and Stephen Terry. (forthcoming). “Does Uncertainty Drive Growth? Using Disasters as Natural Experiments,” Review of Economic Studies.

    • Search Google Scholar
    • Export Citation
  • Bernanke, Ben S. 1983. “Nonmonetary Effects of the Financial Crisis in the Propagation of the Great Depression,” American Economic Review, 73 (3), 257276.

    • Search Google Scholar
    • Export Citation
  • Bernanke, Ben S. 2011. “The Effects of the Great Recession on Central Bank Doctrine and Practice,” Speech at the Federal Reserve Bank of Boston 56th Economic Conference.

    • Search Google Scholar
    • Export Citation
  • Bordo, Michael, Barry Eichengreen, Daniela Klingebiel, and Maria Soledad Martinez-Peria. 2001. “Is the Crisis Problem Growing More Severe?Economic Policy, 16 (32), 5282.

    • Search Google Scholar
    • Export Citation
  • Caggiano, Giovanni., Efrem Castelnuovo, Silvia Delrio, and Richard Kima. 2021. “Financial Uncertainty and Real Activity: The Good, the Bad and the Ugly,” European Economic Review, (forthcoming).

    • Search Google Scholar
    • Export Citation
  • Caprio, Gerard, and Daniela Klingebiel. 1996. “Bank Insolvencies: Cross-Country Experience,” World Bank Policy Research WP 1620.

  • Caprio, Gerard, and Daniela Klingebiel. 2003. “Episodes of Systemic and Borderline Banking Crises.” In Managing the Real and Fiscal Effects of Banking Crises, World Bank, 3149.

    • Search Google Scholar
    • Export Citation
  • Cerra, Valerie, and Sweta Chaman Saxena. 2008. “Growth Dynamics: The Myth of Economic Recovery,” American Economic Review, 98 (1), 439457.

    • Search Google Scholar
    • Export Citation
  • Claessens, Stijn, M. Ayhan Kose, and Marco E. Terrones. 2009. “What Happens during Recessions, Crunches, and Busts?Economic Policy, 24 (60), 653700.

    • Search Google Scholar
    • Export Citation
  • Claessens, Stijn, M. Ayhan Kose, and Marco E. Terrones. 2014. “The Global Financial Crisis: How Similar? How Different? How Costly?In Financial Crises: Causes, Consequences, and Policy Responses, International Monetary Fund, 209237.

    • Search Google Scholar
    • Export Citation
  • Dell’Ariccia, Giovanni, Enrica Detragiache, and Raghuram Rajan. 2008. “The Real Effect of Banking Crises,” Journal of Financial Intermediation, 17 (1), 89112.

    • Search Google Scholar
    • Export Citation
  • Demirgüç-Kunt, Asli, and Enrica Detragiache. 2005. “Cross-Country Empirical Studies of Systemic Bank Distress: A Survey,” IMF WP 05/96.

    • Search Google Scholar
    • Export Citation
  • Gourinchas, Pierre-Olivier, and Maurice Obstfeld. 2012. “Stories of the Twentieth Century for the Twenty-First,” American Economic Journal: Macroeconomics, 4 (1), 226265.

    • Search Google Scholar
    • Export Citation
  • International Monetary Fund. 2017. “Are Countries Losing Control of Domestic Financial Conditions?Chapter 3 of Global Financial Stability Report: April 2017.

    • Search Google Scholar
    • Export Citation
  • Jalil, Andrew J. 2015. “A New History of Banking Panics in the United States, 1825–1929: Construction and Implications,” American Economic Journal: Macroeconomics, 7 (3), 295330.

    • Search Google Scholar
    • Export Citation
  • Jordà, Òscar. 2005. “Estimation and Inference of Impulse Responses by Local Projections,” American Economic Review, 95 (1), 161182.

    • Search Google Scholar
    • Export Citation
  • Kim, Minsuk, Rui Mano, and Mico Mrkaic. 2020. “Do FX Interventions Lead to Higher FX Debt? Evidence from Firm-Level Data.” IMF WP 20/197.

    • Search Google Scholar
    • Export Citation
  • Kroszner, Randall, Luc Laeven, and Daniela Klingebiel, 2007, “Banking Crises, Financial Dependence, and Growth,” Journal of Financial Economics, (84) 187228.

    • Search Google Scholar
    • Export Citation
  • Laeven, Luc, and Fabian Valencia. 2013. “Systemic Banking Crises Database,” IMF Economic Review 61 (2), 225270.

  • Laeven, Luc, and Fabian Valencia. 2014. “Systemic Banking Crises.” In Financial Crises: Causes, Consequences, and Policy Responses, International Monetary Fund, 61137.

    • Search Google Scholar
    • Export Citation
  • Laeven, Luc, and Fabian Valencia, 2020. “Systemic Banking Crises Revisited,” IMF Economic Review 68 (2), 307361.

  • Rajan, Raghuram, and Luigi Zingales. 1998. “Financial Dependence and Growth,” American Economic Review, 88, 559586.

  • Ramey, Valerie A. 2016. “Macroeconomic Shocks and Their Propagation,” NBER WP 21978.

  • Reinhart, Carmen. 2002. “Default, Currency Crises, and Sovereign Credit Ratings,” World Bank Economic Review 16 (2), 151170.

  • Reinhart, Carmen, and Kenneth Rogoff. 2009. This Time Is Different: Eight Centuries of Financial Folly, Princeton University Press.

  • Romer, Christina, and David Romer, 2017, “New Evidence on the Aftermath of Financial Crises in Advanced Countries,” American Economic Review, 107 (10), 30723118.

    • Search Google Scholar
    • Export Citation
  • Schularick, Moritz, and Alan Taylor. 2012. “Credit Booms Gone Bust: Monetary Policy, Leverage Cycles and Financial Crises, 1870-2008,” American Economic Review, 102 (2), 10291061.

    • Search Google Scholar
    • Export Citation
  • Shin, Inseok and Joon-Ho Hahm. 1998. “The Korean Crisis—Causes and Resolution,” KDI Working Paper No. 9805.

  • Sufi, Amir, and Alan M. Taylor. 2021. “Financial Crises: A Survey,” NBER WP 29155.

Figures

Figure 1.
Figure 1.

Financial Stress Index (FSI) over Time

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The Financial Stress Index (FSI) is summing the number of keywords identified with financial stress in EIU country reports. The index is then normalized by total number of words. A higher number means higher financial stress and vice versa. The figure above is an average across 110 countries and covers 1967 to 2018 at a quarterly frequency.
  • 1. Financial stress in 1981Q4 in 6 countries: Argentina, Chile, Costa Rica, Ecuador, Guatemala, and Honduras.

  • 2. Financial stress in 1995Q3 in 11 countries: Alergia, Argentina, Bolivia, Bulgaria, Cameroon, Jamaica, Japan, Liberia, Mexico, Niger, and Paraguay.

  • 3. Financial stress in 1997Q4 in 15 countries: Brazil, Bulgaria, Hong Kong SAR, India, Indonesia, Jamaica, Japan, Korea, Malaysia, Mexico, Paraguay, Philippines, Thailand, Venezuela, and Vietnam.

  • 4. Financial stress in 1998Q4 in 23 countries: Argentina, Brazil, Colombia, Ecuador, Egypt, Hong Kong SAR, India, Indonesia, Jamaica, Japan, Kenya, Korea, Malaysia, Panama, Paraguay, Peru, Philippines, Russia, South Africa, Sri Lanka, Thailand, United States, and Vietnam.

  • 5. Financial stress in 2007Q4 in 19 countries: Austria, Belgium, Brazil, Canada, Denmark, El Salvador, Finland, France, Germany, Iceland, Italy, Netherlands, New Zealand, Norway, Spain, Sweden, Switzerland, United Kingdom, and United States.

  • 6. Financial stress in 2008Q4 in 55 countries: Argentina, Australia, Austria, Belgium, Brazil, Bulgaria, Cameroon, Canada, China, Colombia, Costa Rica, Denmark, Dominican Republic, Ecuador, El Salvador, Finland, France, Gabon, Germany, Greece, Guatemala, Haiti, Honduras, Hong Kong SAR, Hungary, Iceland, India, Indonesia, Ireland, Israel, Italy, Jamaica, Japan, Lebanon, Libya, Netherlands, New Zealand, Norway, Pakistan, Panama, Paraguay, Peru, Portugal, Russia, Singapore, Spain, Sweden, Switzerland, Taiwan Province of China, Thailand, Turkey, United Kingdom, United States, Uruguay, and Vietnam.

  • 7. Financial stress in 2012Q2 in 16 countries: Austria, Belgium, Denmark, France, Germany, Greece, Haiti, Hungary, Ireland, Italy, Netherlands, Nigeria, Pakistan, Portugal, Spain, and United Kingdom.

Figure 2.
Figure 2.

FSI over Time by Country Income Group

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Financial Stress Index (FSI) is summing the number of keywords identified with financial stress in EIU country reports. The index is then normalized by total number of words. A higher number means higher financial stress and vice versa. For the list of countries in each income group, see Table 1. The figure above is an average of three country income levels and covers 1967 to 2018 period at a quarterly frequency.
Figure 3.
Figure 3.

FSI: Average Level vs. Number of Episodes

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Financial Stress Index (FSI) is summing the number of keywords identified with financial stress in EIU country reports. The index is then normalized by total number of words. A higher number means higher financial stress and vice versa. For the list of countries in each income group, see Table 1. The figure above presents FSI averages across income groups and financial stress episodes over the period 1967 to 2018 at a quarterly frequency.
Figure 4.
Figure 4.

FSI over Time by Geographical Region

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The Index of Financial Stress is summing the number of keywords identified with financial stress in EIU country reports. The index is then normalized by total number of words. A higher number means higher financial stress and vice versa. For the list of countries in each region, see Table 1. The figure above is an average over five geographical regions and covers 1967 to 2018 period at a quarterly frequency.
Figure 5.
Figure 5.

FSI vs. other Measures: country examples

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Financial Stress Index is summing the number of keywords identified with financial stress in EIU country reports. The index is then normalized by total number of words, and calculated using a moving average method. A higher number means higher financial stress and vice versa. The data plotted is semi-annual and run from 1967 until 2018, except RR until 2012, ReRo until 2014 and LV until 201
Figure 6.
Figure 6.

Impact of Change in FSI on Output (quarterly data)

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the dynamic response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; cct are country fixed effects; yt are time fixed effects; and ΔF denotes the change in FSI.
Figure 7.
Figure 7.

Impact of Change in FSI on Output—Advanced Economies (AE) vs. Emerging Markets and Developing Economies (EMDE)

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, and are based on yi,t+k=αik+γtk+Σj=02βjkΔAEi,tj+Σj=02jkΔEMDEi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αt are country fixed effects; γt are time fixed effects; and ΔAE denotes the change in FSI in Advanced Economies (AE) and ΔEMDE denotes the change in FSI in Emerging Markets and Developing Economies (EMDE).
Figure 8.
Figure 8.

Impact of Change in FSI on Output—Non-linear Effects

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, based yi,t+k=αik+γtk+β0kG[FitG]ΔEi,t+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where I is an indicator function which assumes value 1 when the level of financial stress belongs to a specific bin (terciles) of the distribution, which we refer to as group G.
Figure 9.
Figure 9.

Robustness Checks—Alternative Samples

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αt are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. The plots above consider dropping: a) outliers (those observations corresponding to the residuals in the output regression at the bottom and top percentiles of the distribution); b) high inflation episodes (inflation above 20 percent); c) observations from the Americas; d) Asian and Sub-Saharan African economies; e) small economies (with population below two millions); f) episodes of large changes in financial stress episodes (those corresponding to the 99th percentile of the distribution); and g) excluding the period following the Global Financial Crisis (after the third quarter of 2008).
Figure 10.
Figure 10.

Robustness Checks—Alternative Sets of Control Variables

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+Σj=02θjkXi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; ΔF denotes the change in FSI; and X is a set of controls as follows: i) without lag of FSI; ii) overall balance (% of GDP); iii) short-term interest rate (%); iv) uncertainty; v) log stock return volatility; and vi) stock return (%).
Figure 11.
Figure 11.

Impact of Change in FSI on Output (annual data)

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using the full sample of 110 countries over the period 1967–2018 (Panel A), and the sample used for the quarterly data baseline equation (Panel B). Both panels are based yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to years, and k denotes the horizon (the year after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; αt are time fixed effects; and ΔF denotes the change in FSI.
Figure 12.
Figure 12.

Impact of Change in FSI and Alternative Chronologies

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates of baseline are obtained using a sample of 25 countries for the analysis based on the Romer&Romer sample, and of 105 countries for the others analysis over the period 1967–2018, and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the years after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI.
Figure 13.
Figure 13.

Impact of Change in FSI on Output—IV results

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in financial stress. The instrumental variable (IV) approach consist of ΔFi,t=πt+τt+ϑΔEFi,t+Σj=02ρjkΔFi,tj+Σj=02σjkyi,tj+μt, whereas EFi,t is the indicator of external financial stress produced using the information on episodes of external financial stress.
Figure 14.
Figure 14.

Results—Excluding G7 Economies and China

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. The instrumental variable (IV) approach consist of ΔFi,t=πt+τt+ϑΔEFi,t+Σj=12ρjkΔFi,tj+Σj=02σjkyi,tj+μt, where EFi,t is the indicator of external financial stress. Excluding the G7 countries and China one at a time
Figure 15.
Figure 15.

IV Results—Controlling for Growth in Major Trading Partners

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. The instrumental variable (IV) approach consist of ΔFi,t=πt+τt+ϑΔEFi,t+Σj=12ρjkΔFi,tj+Σj=02σjkyi,tj+Σj=02θjkforeigngi,tj+μt, where EFi,t is the indicator of external financial stress, and foreign_gi,t-j is the growth in major trading partners.
Figure 16.
Figure 16.

IV Results—Annual Data

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 110 countries over the period 1967–2018 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk where ‘index countries, t refers to years, and k denotes the horizon (the year after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. The instrumental variable (IV) approach consist of ΔFi,t=πt+τt+ϑΔEFi,t+Σj=12ρjkΔFi,tj+Σj=02σjkyi,tj+μt, whereas EFif is the indicator of external FSI.
Figure 17.
Figure 17.

Impact of Change in FSI on Output—Advanced Economies (AE) vs. Emerging

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, and are based are based on yi,t+k=αik+γtk+β0kAEDΔFi,t+β0kEMDE(1D)ΔFi,tjΣj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. where D is a dummy variable which takes value 1 for AE, and zero otherwise..
Figure 18.
Figure 18.

Impact of Change in FSI on Output—Non-linear Effects

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, based on yi,t+k=αik+γtk+β0kGI[FitG]ΔFi,t^+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where I is an indicator function which assumes value 1 when the level of financial stress belongs to a specific bin (terciles) of the distribution, which we refer to as group G.
Figure 19.
Figure 19.

Impact of Change in FSI on other Macroeconomic Variables

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is: (i) stock returns %; (ii) log (stock returns volatility); (iii) World Uncertainty Index (wui); (iv) unemployment; (v) employment; and (vi) labor productivity; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI.
Figure 20.
Figure 20.

Impact of Change in FSI on other Macroeconomic Variables—IV Results

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4, and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is: (i) stock returns %; (ii) log (stock returns volatility); (iii) World Uncertainty Index (wui); (iv) unemployment; (v) employment; and (vi) labor productivity; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI.
Figure 21.
Figure 21.

Impact of Change in FSI on Firm Investment

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Note: Impulse response functions based on local projection methods following Jordà (2005) using firm-level quarterly data from 75 countries for the period 2001Q1 to 2020Q4. Estimates based on the regression yn,i,t+k=αisk+γnqk+Σj=02βjkΔFi,tj+Σj=12θjkyn,i,tj+εn,i,tk for different horizons ‘£’, where yn,i,t+k is the log change in capital expenditure of firm n in country i at time t over the next k quarters, ΔFi,t-j is the change in FSI, γnqk are firm-quarters fixed effects, and αisk are country-sector fixed effects. The regression is estimates separately for different horizons k (for up to 12 quarters). The solid line shows the point estimate for β0k for different horizons k, while the dotted lines are the 68 percent and 90 percent confidence intervals. Standard errors are clustered at two-way at the firm and country-time level.
Figure 22.
Figure 22.

Impact of Change in FSI on Firm Investment—the Role of Firm Characteristics

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Note: Impulse response functions based on local projection methods following Jordà (2005) using firm-level quarterly data from 75 countries for the period 2001Q1 to 2020Q4. Estimates based on the regression yn,i,t+k=αistk+γnqk+Σj=k2μjkΔFi,tj+Dn+Σj=12θjkyn,i,tj+εn,i,tk for different horizons ’k’, where yn,i,t+k is the log change in capital expenditure of firm n in country i at time t over the next k quarters, ΔFi,t-j is the change in FSI, γnqk are firm-quarters fixed effects, and αisk are country-sector fixed effects. The regression is estimates separately for different horizons k (for up to 12 quarters). The solid line shows the point estimate for β0k for different horizons k, while the dotted lines are the 68 percent and 90 percent confidence intervals. Standard errors are clustered at two-way at the firm and country-time level.
Figure 23.
Figure 23.

Impact of Change in FSI on Firm Investment—the Role of Firm characteristics (IV)

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Note: Impulse response functions based on local projection methods following Jordà (2005) using firm-level quarterly data from 75 countries for the period 2001Q1 to 2020Q4. Estimates are based on the regression yn,i,t+k=αistk+γnqk+Σj=k2μjkΔFi,tj+Dn+Σj=12θjkyn,i,tj+εn,i,tk for different horizons ’k’, where ynM+k is the log change in capital expenditure of firm n in country i at time t over the next k quarters, ΔFi,t-j is the change in FSI, γnqk are firm-quarters fixed effects, and αisk are country-sector fixed effects. The regression is estimates separately for different horizons k (for up to 12 quarters). The solid line shows the point estimate for β0k for different horizons k, while the dotted lines are the 68 percent and 90 percent confidence intervals. Standard errors are clustered at two-way at the firm and country-time level.

Tables

Table 1.

Data Coverage: FSI vs. other Chronologies

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Notes: The table reports country and time coverage across 4 financial stress indicators. It also provides the definition and method used to arrive at the financial stress variable constructed.
Table 2.

Pair-wise Correlations between Chronologies

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Notes: The table reports correlations for each pair of the 4 financial stress indicators.
Table 3.

Impact of Change in FSI on Output (quarterly data)

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Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996ql-2018q4 and are based on: yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in FSI) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI.
Table 4.

Impact of change in FSI on Output (annual data)

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Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1,5 and 10 percent, respectively. Estimates are obtained using a sample of 110 countries over the period 1967–2018 and based on: yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to years, and k denotes the horizon (the year after the change in FSI) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI.
Table 5.

Foreign Shocks—Reverse Causality

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Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on EFi,t+k=αik+γtk+Σj=12βjkEFi,tj+Σj=02βjkΔlngdpi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. EF is the foreign shock; αi are country fixed effects; γt are time fixed effects; and Δlngdp is the change in the log of output.
Table 6.

Adding the Instrument as a Control Variable

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Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996ql-2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+jkCi,tj+εtk where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI, and EFi,t refers to the instrumental variable.
Table 7.

Validity of the Instrument (Regressing instrument on residuals of baseline)

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Notes: Standard errors clustered at the country-level in parenthesis. ***, **, * denote statistical significance at 1, 5 and 10 percent, respectively. Estimates are obtained using a sample of 49 countries over the period 1996q1–2018q4 and are based on yi,t+k=αik+γtk+Σj=02βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered. y is the log of output; αi are country fixed effects; γt are time fixed effects; and ΔF denotes the change in FSI. Subsequently, by taking the residual from the baseline and checking the validity of the instrumental variable, estimates are obtained based on residi,t+k=αik+βjkΔEFi,t+εtk, where resid is the residual obtained from the baseline and EFi,t is the indicator of external financial stress used as an instrument.

Appendix

Table A1.

Country Coverage across Income Levels and Geographical Regions

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Note: The table presents country coverage of the index across income levels and geographical regions. Font in blue = advanced economies, red = emerging economies, and black = low-income economies.
Table A2.

Financial Distress: Examples of Type of Discussion in EIU Reports, 1967–2018

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Table A3.

Financial Stress Dates: FSI vs. 8 other Measures Countries: Afghanistan to Botswana

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Notes: “*” indicates that only start date available. “-” indicates that it is not within the country and/or time coverage of the respective study. Laeven & Valencia column is based on Table 1 and 2 of Laeven and Valencia (2020), Romer & Romer column is based on Table 2 of the online appendix of Romer and Romer (2017), Reinhart & Rogoff column is based on the online reference of banking crisis of Reinhart and Rogoff (2009), Caprio & Klingebiel column is based on pages 32 to 48 of Caprio and Klingebiel (2003), Demirguc-Kunt & Detragiache column is based on Table 2 of Demirguc-Kunt and Detragiache (2005), Schularick & Taylor is based on table Al of the web appendix of Schularick and Taylor (2012), Bordo, Eichengreen, Klingebiel and Martinez-Peria is based on Appenx A of Bordo et al (2001), and Boron, Verner & Xiong column is based on Appendix Table 2 of Baron et al (2018).
Table A4.

Impact of Change in FSI on Output—Non-linear Effects. P-value differences in responses

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Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996ql-2018q4, based on yi,t+k=αik+γtk+β0kGI[FitG]ΔFi,t+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where I is an indicator function which assumes value 1 when the level of financial stress belongs to a specific bin (terciles) of the distribution, which we refer to as group G.
Table A5.

External Financial Stress: Examples of Type of Discussion in EIU Reports

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Table A6.

Sample of 75 Countries by Geographical Region

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Table A7.

Number of Firms and Observations by Country

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Table A8.

Number of Firms and Observations by Sector

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Figure A1.
Figure A1.

Impact of Change in FSI on Output—Non-linear Effects

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996ql-2018q4, based on yi,t+k=αik+γtk+β0kGI[FitG]ΔFi,t+Σj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where I is an indicator function which assumes value 1 when the level of financial stress belongs to a specific bin (terciles) of the distribution, which we refer to as group G.
Figure A2.
Figure A2.

Impact of Change in FSI on Output—Non-linear Effects

Citation: IMF Working Papers 2023, 217; 10.5089/9798400257636.001.A001

Notes: The graph shows the response and shaded areas denote 90 percent confidence bands. Time is indicated on the x-axis. Estimates are obtained using a sample of 49 countries over the period 1996ql-2018q4. Panel A is based on yi,t+k=αik+γtk+β0kHDΔFi,t+β0kL(1D)ΔFi,tjΣj=12βjkΔFi,tj+Σj=02θjkyi,tj+εtk, where i index countries, t refers to quarters, and k denotes the horizon (the quarter after the change in the financial stress indicator) being considered, y is the log of output; αt are country fixed effects; γt are time fixed effects; and ΔF denotes the change in financial stress. D is a dummy variable which takes value 1 if the level of FSI is above the median of the distribution, and zero otherwise. The coefficients βkH and βkL capture the output impact of financial stress at horizon k in cases of low levels of FSI and high levels of FSI, respectively. An alternative specification is in Panel B based on yi,t+k=αik+γtk+F(zit)[β0kHΔFi,t]+(1F(zit))[β0kLΔFi,tj]+Σj=02θjkyi,tj+εtk, with F(zit)=expγzit1+expγzit where γ = 1.5.
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3

In an update the authors add 6 countries that joined the OECD between 1994 and 2000 and extend the sample to 2017.

4

Our literature review focuses on measures of financial stress. We do not provide a comprehensive literature of the studies examining asymmetric effects of financial stress on future GDP growth. For example, Adrian et al. (2022), using panel quantile regressions for 11 economies, explore how different states of the economy can potentially interact with financial conditions in nonlinear ways in forecasting the GDP growth distribution at different time horizons.

5

For over a decade, the Laeven-Valencia dataset has been used in hundreds of applications and received thousands of citations in both academic and policy journals.

6

See Ahir, Bloom and Furceri (2022) who also used EIU for constructing an index on economic uncertainty.

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See Appendix Table A1 for country coverage by income level and geographical region.

8

In our future work we plan to use the EIU availability at the monthly frequency starting in 2008 and covering a smaller sample of (about 70) countries, as well as will include alternative versions of FSI that reflect sub-dimensions of financial stress. See Ahir, Bloom and Furceri (2022) for a similar approach.

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Appendix Table A2 reports country-by-country and period-by-period examples of EIU narratives identified as related to financial distress.

10

As discusses in Ahir, Bloom and Furceri (2022), while the number of words is on average larger in advanced economies than in emerging and low-income countries, there are no systematic differences across income groups. For example, country reports for countries such as Nigeria or Egypt have a larger number of pages (words) than many advanced economies.

11

For brevity we focus only on three alternative chronologies. Appendix Table A3 provides detailed country-by-country coverage comparison of our measure with 8 alternative measures in the literature.

12

For comparisons between FSI and RR, ReRo, and LV chronologies for all 110 countries in our sample see Appendix Figure A3.

13

According to official documents of June 1983, Honduras had accumulated 75% of GDP in total foreign debt. During the same period 8 other Latin American countries had foreign debt ranging from 75%-134% of GDP. During the 1980s, a period often referred to as “the lost decade’’, many Latin American countries were unable to service their foreign debt.

14

The FCI is computed as the principal component of several financial variables such as interest rates, sovereign and corporate debt spreads, equity prices and volatility, exchange rate volatility and real house prices; it covers and unbalanced sample of 43 advanced and emerging market economies from 1996Q1.

15

Panel cointegration tests reject the null hypothesis that the estimated residual of Equation (1) is non-stationary.

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The differences in the responses in these two approaches is statistically significant only in the short term but not in the medium term because of the large confidence bands associated with the medium-term point estimates for the low-financial stress regime. In addition, differences are more noticeable for EMDEs than AEs (see Figure A1). Finally, and consistent with Romer and Romer (2017), we do not find evidence that the effect of financial stress output depends linearly on the level of financial stress.

17

Similar results are obtained when excluding the period after the fourth quarter of 2007, or after 2009.

18

See the Appendix Table A5. for the list of episodes and the associated narrative.

19

We also re-estimated Equation (1) using external financial stress directly as main regressor, instead of as instrument for overall financial stress. The results are qualitatively unchanged. See Ramey (2016) for a discussion on using macroeconomic variables as shocks or instruments in VAR and Local Projection settings.

20

Similar results are obtained when we consider the median of the sector, and the median of the sector within each country.

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Financial Stress and Economic Activity: Evidence from a New Worldwide Index
Author:
Hites Ahir
,
Mr. Giovanni Dell'Ariccia
,
Davide Furceri
,
Mr. Chris Papageorgiou
, and
Hanbo Qi