Latin American Banking Fragility: An Assessment of the Role Played by Foreign Banks Lindsay Jones and Stefan Krause∗ August 2007 Abstract The purpose of this paper is to determine whether foreign bank presence has had a stabilizing or destabilizing effect on the Latin American banking sector. Our results suggest that, while "brick and mortar" operations of foreign banks in Latin American countries contribute to the reduction of the probability of a banking crisis, there is no significant effect of direct foreign lending initiated outside the country on the likelihood of experiencing financial distress. JEL classification: F34, G21, O54 Keywords: banking crises, foreign banks, credit growth ∗ Department of Economics, Emory University. Please send comments to skrause@emory.edu. 1 Introduction In regions such as Latin America, where capital markets and alternative sources of fi- nancing are not yet well developed, banks are largely responsible for the efficient allocation of resources and credit in the domestic economy. Banking institutions in these countries, therefore, play an integral role in determining economic progress. Over the past three decades, however, banking crises and general banking instability have been a recurring source of distress for the region, with numerous countries experiencing problems (see Table 1 for a list of crises since the early 1980s). These banking problems are often widespread, affecting not only individual banks, but whole banking sectors, and threatening the solvency of many countries’ entire banking industry, as contended by Peek and Rosengren (2000). Because of their systemic nature, banking crises have had severe financial repercussions for afflicted economies, resulting in budgetary costs totaling as much as 55% of GDP.1 More importantly, because long-run economic growth has been found to be linked to the strength and depth of the financial sector, as discussed by Levine (1997), problems in the banking system, an integral component of that sector, can take a significant macroeconomic toll and severely disrupt economic development in emerging markets. Another relevant trend in Latin America’s banking sector over the past two decades has been an increasing importance of foreign bank financing. Although this has been true for many emerging market economies, the trend is especially prominent in Latin America. According to a study by the International Monetary Fund (IMF, 2000), the share of banking assets held by foreign controlled banks in Latin America rose from 7.5 percent in 1994 to 25 percent in 1999. As a percentage of domestic credit, the claims of Bank of International Settlements’ (BIS) reporting banks, another indicator of foreign bank presence, has also increased dramatically over a period of twelve years, rising from 2.4 percent in 1993 to 30.2 percent in 2004 (see Figure 1). The theory about the possible effects of foreign ownership is inconclusive, as there are equally plausible reasons why foreign bank entry might be both 1 See Caprio and Klingebiel (1996), and Hoggarth, Reis and Saporta (2002). 1 beneficial and harmful. The purpose of this paper is to determine whether foreign bank presence has had a stabilizing or destabilizing effect on the Latin American banking sector by examining its effect on the probability of a banking crisis. We concentrate on Latin America for several reasons. First, banking crises in this region have been extremely common during the period in question, which makes a study of the causes and possible solutions to these crises very relevant. Second, the general macroeconomic volatility of the region can have adverse effects on its banks, and strategies to cope with this volatility, such as openness to foreign bank entry, could therefore prove quite valuable. Third, with respect to foreign bank presence, Latin America is an ideal region for empirical analysis due to the fact that it is one of the areas that exhibits both a substantial change in foreign bank participation, and a significant amount of variability across countries in terms of the relative importance banks of overseas have on domestic financial markets. We use a multivariate probability model in order to determine the effect of foreign bank presence on the probability of experiencing a banking crisis. This regression also includes various macroeconomic and financial variables as controls, and we investigate their respective effects. Of particular interest is the role played by credit growth, since financial liberalization and lending booms have been of particular importance in prompting crises in Latin America.2 Nevertheless, this hypothesis has not been investigated for this region in isolation, and as argued by Caprio and Klingebiel (2000), the link between credit growth and banking crises diminishes when a broader sample is examined. Since the mid-1990s, much empirical research has been devoted to exploring the causes and characteristics of banking crises. Foreign bank entry has also been the subject of many studies. However, since most research has considered the two subjects independently, we hope to contribute to the literature by simultaneously examining the effect of foreign bank entry on banking sector stability and probability of crisis. 2 See Díaz-Alejandro (1985), De Gregorio and Guidotti (1995), and Gavin and Hausman (1998), among others. 2 With respect to banking crises, no consensus has been reached regarding the factors that definitively contribute to the emergence of financial distress. As stated earlier, distortions in the banking sector can contribute to macroeconomic instability; however, the causal arrow may actually point in both directions, with some studies showing macroeconomic shocks to be a central cause of banking crises. Alternatively, others find structural and institutional characteristics of the financial sector to be more significant contributors to crises. In general, debates such as this one are yet to be settled, making crisis prevention analysis nearly impossible. Demirgüç-Kunt and Detragiache (1998) find the domestic macroeconomic environment to be of particular importance in predicting banking crises, noting that low growth, high inflation, and high real interest rates often precede crises. Another study by Eichengreen and Rose (1998) also takes a macroeconomic approach; however, the authors argue that adverse external conditions, as opposed to domestic factors, play the most important role in triggering emerging markets banking crises. Specifically, they find that a rise in industrial country interest rates can precipitate a crisis due to developing country banking systems’ subsequent lack of access to international funds. Several theoretical and empirical studies have examined the effect of the regulatory and institutional environment on probability of crises and overall macroeconomic performance. Corsetti, Pesenti and Roubini (1999) derive a model of financial crisis that focuses on moral hazard as the common source of overinvestment, excessive borrowing, and current account deficits in an economy with a poorly supervised and regulated financial sector. DemirgüçKunt and Detragiache (1999, 2002) argue that the relationship between financial liberalization, financial development and growth should be analyzed cautiously whenever prudential regulation and supervision are not fully developed. Furthermore, they find evidence suggesting negative effects of financial development on growth for twelve Latin American countries, and argue that the negative effect is the result of financial liberalization in a poor regulatory environment. 3 Finally, Barth, Caprio and Levine (Barth et al, 2001) find that tighter restrictions on bank activities and bank ownership increase the likelihood of crises; moreover, they find that neither of these restrictions produces beneficial effects on financial development. The importance of regulation could indicate that openness to foreign bank ownership might prove beneficial to banking sector stability and macroeconomic performance, although this connection has not been directly examined in the literature to date. The main conclusion to be extracted from the aforementioned studies is that banking crises likely result from a combination of factors: macroeconomic, institutional, domestic, and international. In a region as volatile as Latin America, it is likely that macroeconomic pressures make crises possible by placing tension on an already vulnerable banking system. The question, then, is which aspects of the banking environment can be instrumental in reducing volatility and susceptibility to macroeconomic pressures. Openness to foreign bank ownership has been suggested as one factor that might contribute to reducing macroeconomic vulnerability in emerging market countries. In one of the first panel studies on the issue, Martinez Peria, Powell, and Vladkova (Martinez Peria et al., 2002) investigate the stability of foreign bank claims in Latin America and find that, although banks may transmit shocks from their home countries, this effect becomes diminished as their exposure to the host country increases. They also find that foreign lending is not necessarily curtailed during times of domestic instability and crisis. Other studies have similarly shown that foreign bank presence in developing countries plays a beneficial role in the stability of the domestic banking sector. For example, Caprio and Honohan (2003) find use short term aggregate balance sheet data to show that banking systems with greater foreign ownership are more stable when faced with macroeconomic shocks. Similarly, Hermes and Lensink (2004) examine the effect of foreign bank entry on domestic bank performance and find that for low levels of financial development, increased foreign bank presence can increase the costs and margins of domestic banks, while for higher levels of financial development, foreign banks tend to have the opposite effect. These studies 4 do not, however, directly investigate the link between foreign banks and banking crises. Thus, we intend to build upon the existing literature by studying the effect of foreign banks in Latin America with regard to financial sector instability and crisis. The remainder of this paper is organized as follows. In Section 2 we further discuss the role that the presence of foreign banks play in the development of financial markets; and formalize the model to be estimated. Section 3 provides a description of the data set and the main variables of interest; in particular, we focus on the distinction between financing by foreign banks stemming from “brick and mortar” operations in local currency, and financing denominated in foreign currency. In Section 4 we present and analyze our main findings: our results suggest that, while “brick and mortar” operations of foreign banks in Latin American countries significantly contribute to the reduction of the probability of a banking crisis, the effect of direct foreign lending initiated outside the country is not a significant determinant of financial distress. Finally, Section 5 concludes and explores some policy implications. 2 The Role of Foreign Bank Presence As stated in the introduction, foreign bank entry could have both positive and nega- tive effects on Latin American countries’ banking sectors.3 Foreign banks are a potentially destabilizing influence on the domestic banking system for several reasons. Disturbances stemming from the banks’ home economies might affect their behavior in the host country, and foreign banks might retrench during domestic banking disturbances by shrinking operations in host countries or by withdrawing completely. Thus, foreign banks are thought to stimulate capital flight due to a lack of commitment to the host country. Also, Lensink and Hermes (2004) show that, at relatively low levels of economic development, foreign bank entry is associated with higher costs and margins for domestic banks. Finally, as argued by Stiglitz (1993), if the competition from foreign banks weakens domestic banks, monetary and 3 Claessens, S., A. Demirgüç-Kunt and E. Detragiache provide an exhaustive review on the effects of the international expansion of banks. 5 regulatory authorities will be less able to affect bank behavior, as foreign banks will become unresponsive to domestic credit needs. Conversely, foreign banks may indeed contribute to greater banking sector stability in several important ways. First, some believe that they are actually less affected by domestic shocks, thereby providing more stable sources of financing during times of domestic disturbance than domestic banks. In this way, they certainly would not stimulate capital flight, but rather would perform better than domestic banks during stressful times. Additionally, foreign banks can be a good source of funds for recapitalization of banks in the aftermath of a crisis. Finally, foreign banks usually bring advanced technologies to the host country, which can lead to improvements in the domestic banking sector as a whole.4 Since theory on foreign bank entry in developing countries is inconclusive, empirical analysis is essential in determining foreign banks’ effects on Latin American banking sector stability. In general, we expect the results to show foreign banks to be a stabilizing force in the region for several reasons. First, the argument that foreign banks might stimulate capital flight due to negative host shocks has been refuted in several previous empirical studies of emerging markets.5 These studies show that foreign claims are relatively stable during times of domestic disturbance, indicating indeed that foreign banks might be more reliable than domestic banks. Second, it has been empirically shown that foreign banks have become less likely over time to transmit shocks from their home countries, as documented by Martinez Peria, et al. (2002). Third, foreign bank entry into emerging markets with relatively less developed financial sectors has been shown to improve domestic banking efficiency, thereby improving the overall quality of the banking sector as argued by Demirgüç-Kunt and Detragiache (1998). Therefore, due to the compelling evidence supporting the view that foreign banks can be a positive influence, we predict the results to indicate a negative correlation between foreign bank presence and probability of a banking crisis. In order to identify the effect of foreign bank presence on banking sector stability, we 4 5 For a more detailed discussion of these arguments, see Peek and Rosengren (2000). See Martinez Peria, et al (2002), and Caprio and Honohan (2003) for an in-depth analysis. 6 follow the general model employed in several other previous analyses,6 and utilize a multivariate probability model with panel data. Specifically, we use a logit model in which the probability of a systemic banking crisis is a function of multiple explanatory variables, including a measure of foreign bank influence. The general specification of the model is as follows: P r(Yit = 1) = F (αi + β 1 F oreignit + β 2 Creditit + β 3 Zit + εit ) , (1) where F oreign is one of the measures of foreign bank presence, as described below; Credit is a measure of credit growth; Z is a set of macroeconomic control variables; α represents a country-specific effect; and ε is an error term. In the first set of regressions, the dependent variable include all years for which a banking crisis is in place. However, the behavior of some of the explanatory variables, such as credit growth, GDP growth, and interest rate, is quite probably affected by a crisis, which could skew the results. Thus, following Demirgüç-Kunt and Detragiache (1998), we run an alternative set of regressions, where all years during which a crisis is ongoing are excluded. We discuss this issue in more detail on Section 4. 3 Data Description To determine years of financial crises, we use Caprio and Klingebiel’s 2003 World Bank database, which identifies and dates 117 systemic banking crises, defined as all or much of bank capital being exhausted, for the years 1970 through 2002. The crisis variable takes a value of one if the country is experiencing the first year of a systemic crisis and zero otherwise. In order to measure foreign bank presence, we use data from the Bank of International Settlements (BIS) consolidated banking statistics, as detailed in the Data Appendix. Foreign banks can provide financing to Latin American countries through two channels. The first is to establish “brick and mortar” branches and subsidiaries inside the countries, providing 6 See, for example, Demirgüç-Kunt and Detragiache (1998), Eichengreen and Rose (1998), and Barth et al (2001). 7 financing using local funding. The second is to directly finance from their headquarters outside the region (Martinez Peria et. al., 2002). In order to capture both sources, we run separate regressions using two different measures of foreign bank influence. The first, which we denote by Local Foreign, is the amount of local claims of BIS reporting banks denominated in local currency. This measure captures the local financing from “brick and mortar” operations. Nevertheless, it includes not only claims on the private sector, but also claims on the public sector, and it also excludes direct foreign lending in other currencies. Finally, local currency claims represent less than half of total foreign claims and therefore may not be an appropriate measure of foreign bank presence. The second measure we include, denoted by International Foreign, is the amount of international bank claims on the non-bank private sector. This measure reports cross-border claims and claims on local residents denominated in foreign currencies and therefore includes direct foreign lending. It is worthwhile to note that this measure excludes public sector lending, and that it does not capture local currency lending by foreign banks’ “brick and mortar” affiliates. Finally, in order to control for macroeconomic factors, we include the real GDP growth rate, CPI inflation, and nominal exchange rate devaluation. We also include a measure of credit growth, which is given by the percent change in total credit to the private sector. Finally, a trend variable is included to account for factors that are common to the countries in our sample. The sources for this data are the World Bank Development Indicators and the International Financial Statistics. In general, our controls are similar to the ones commonly employed in several empirical studies,7 with two principal differences. First, we employ bank liquidity (measured by the ratio of bank reserves to bank assets) and the ratio of M2 to reserves as instruments for the foreign bank presence variables, instead of using them directly as controls. Second, due to data limitations, we do not include the results when controlling for the real interest rate, 7 See Demirgüç-Kunt and Detragiache (1998), and Buyukkarabacak and Valev (2006), among others. 8 the terms of trade, and the current account balance, since the sizeable reduction in the sample poses a problem in terms of providing a direct comparison of the results. We further elaborate these latter points in Section 4. Combining the above described data sources results in a panel of 10 Latin-American countries (that experienced banking crises), for a period of 23 years (i.e., between 1982 and 2004).8 In Section 4 we proceed to present and discuss the impact (if any) that foreign banks have had in the onset or prevention of financial sector crises. 4 Results 4.1 Baseline Specification We estimate the effect of foreign bank presence on the probability of a banking crisis using a country-specific fixed effects logit estimation, since our specification tests provide us with strong evidence to prefer the individual country effects over a pooled regression. We believe that this is indicative of idiosyncrasies in the likelihood that a given country will experience a period of financial distress. The main results of estimating equation (1) are presented in Tables 2 through 5. The first three columns of Table 2 report the regression analysis using the Local Foreign bank measure as the explanatory variable, while controlling for two lags of private credit growth, GDP growth and a common time trend. Local Foreign appears in all regressions with a negative and significant (to the 5% level) coefficient. This suggests that brick and mortar operations by foreign banks can be a mitigating factor in the onset of a potential banking crisis, consistent with the claim that a larger participation by foreign banks in financing private credit may indeed contribute to greater banking sector stability. Turning to the control variables, in all specifications the coefficient on real GDP growth is negative and significant (at the 1% level), indicating that a boost in aggregate economic 8 Unfortunately, from the 12 countries listed on Table 1, the data on Colombia’s and Peru’s episodes could not be used, since they experienced crises starting in 1982 and 1983, respectively. 9 activity may play a significant role in reducing the probability of crisis. However, even though the coefficients on inflation and devaluation are positive (as expected), neither of these factors appear to be significantly associated with a higher probability of financial distress.9 These results suggest that the domestic macroeconomic environment is indeed important in explaining crises, as argued by Demirgüç-Kunt and Detragiache (1998), with real variables playing a more relevant role than nominal variables. Finally, private credit growth is positively correlated with the probability of a crisis. Since Latin America has not previously been considered in isolation, these results support recent literature findings that suggest how credit booms might be of importance in prompting crises in the region. Gavin and Hausman (1998) argue that periods of credit expansion can lead to a decline in the quality of bank assets, which contributes to vulnerability by worsening bank portfolios. This decline in asset quality is largely due to information problems: during times of abundant credit, it might be more difficult for banks to distinguish between good and bad credit risks. Additionally, the speed of portfolio growth during a lending boom may further worsen banks’ information problems because managers may rapidly seek out new clients about whom they have little information. Thus, credit booms can increase the risk of banks’ portfolios, which contributes to instability and can ultimately lead to a crisis. Noticeably, the effect of a lending expansion is largest and most significant when the credit boom considered is the one taking place two years prior. This observation may indicate that instead of a rapid boom and bust phenomenon, the accumulation of credit - and, tangentially, the gradual worsening of bank portfolios - may take slightly longer to become visible and to directly affect the banking system in the form of financial distress.10 The International Foreign regressions reported on Tables 3 and 5, however, provide less 9 Also, using a more restricted sample, we find evidence suggesting that the real interest rate is positively and significantly correlated with a crisis, consistent with the theory that the banking system can be vulnerable to interest rate shocks when the interest paid by banks on deposits increases, exceeding the rate of return on assets. These results are available upon request from the authors. 10 We note that employing the one-lag or the two-lag private credit growth variables separately does not change our main findings: The coefficients on Local Foreign and real GDP growth remain negative and significant, while the effects continue to be largest when considering the two-lagged value of credit growth versus the one-lagged value. These additional results are available upon request from the authors. 10 convincing support for the argument that foreign bank presence lowers the likelihood of a crisis. International Foreign takes a positive sign in several of the specifications; however, its coefficient is never significant. Thus, the effect of this type of foreign lending on the probability of financial distress is less certain. These results are sensible when one considers the differences between each of the measures of foreign presence. Since Local Foreign measures claims in local currency, it mostly captures foreign presence in the form of brick and mortar operations within the host country. Intuitively, it is not surprising that this form of foreign presence would be comparatively steadier, and thus contribute more to banking sector stability, than direct cross border lending, which is captured best by International Foreign. With regard to the theory, this latter type of lending by foreign banks is likely easier to be withdrawn in stressful times. This is not to say, however, that this withdrawal would definitely occur. Thus, although the results do not as strongly suggest that it is always a stabilizing influence, direct cross-border financing is not necessarily destabilizing, either. 4.2 Robustness Exercises We need to acknowledge that the extent to which foreign banking is present in an economy may be affected by the onset of a banking crisis, thereby leading to potential endogeneity problems. One option is for both Local Foreign and International Foreign to enter the regressions with one- or two-year lags. Alternatively, we can employ an instrumental variable approach to maintain the integrity of our model specification in equation (1). We combine these two approaches and instrument for both foreign bank presence variables using one- and two-year own lags, a one-year lag of real GDP growth, and control for differences in the banking system: Bank liquidity and the ratio of M2 to reserves. The results of this IV-approach are reported in columns 4 through 6 of Tables 2 and 3, for the Local Foreign and International Foreign measures, respectively. The IV-estimation reinforce our previous findings: Local Foreign presence remains a significant (now at the 1% level) variable in reducing the probability of a banking crisis; 11 while the coefficient of International Foreign, even though it becomes positive and larger in absolute terms, is still insignificant. The results on the control variables are also unchanged: real GDP growth still enters the regression with a negative and significant coefficient, while inflation and devaluation have no perceptible effect on the probability of financial turmoil. Since determining the end date for a crisis period can be somewhat arbitrary, we perform a robustness check by running another set of regressions in which all years during which a crisis is ongoing are excluded. Tables 4 and 5 report analogous regression results to the ones in Tables 2 and 3, respectively, but exclude observations during which crises are on-going. The main findings are once again unchanged: While Local Foreign enters the regression with a negative and significant sign, the coefficient on International Foreign remains insignificant. This result also holds when employing the IV-estimation. 4.3 Implications In general, the above results support the hypothesis that foreign bank entry in emerg- ing markets can have positive effects on the domestic banking system. This hypothesis states that foreign banks might constitute a more stable source of financing during domestic macroeconomic disturbances and that they can improve domestic banks by bringing new technology. Indeed, both of these effects would likely contribute to stability as a whole, as indicated by the results. Conversely, the results does not find any evidence that foreign banks can have destabilizing effects on the banking system by transmitting disturbances from their home country or retreating during times of domestic disturbance. In terms of policy implications, GDP growth and foreign bank presence, especially in the form of brick and mortar operations, seem to be “blue flags” as to the prevention of a banking crisis. The most relevant “red flag” for policy makers to monitor is rapid credit growth, which is associated with a significant increase in the probability of a crisis in Latin America, consistent with the findings of Demirgüç-Kunt and Detragiache (1998), and Buyukkarabacak and Valev (2006) for a broader sample of countries. The fact that inflation and depreciation 12 are insignificant across all specifications seems to indicate that these variables are not as relevant with respect to the prevention of financial distress in Latin American countries. 5 Conclusions In this paper we address several questions with respect to the roots of Latin American banking crises and the role played by foreign banks. In a region as volatile as Latin America, low GDP growth and unsustainable private credit growth are contributing factors to potential financial turmoil. However, we find that foreign banks can be a mitigating factor and be instrumental in reducing the vulnerability of the domestic banking system, thereby lessening the chance of a resultant crisis. These findings must be interpreted with care, however, as the dependent banking crisis variable might present certain problems. Because it is a discrete variable, it is impossible to objectively and qualitatively distinguish between crises of varying extremity. All observations are classified as either “crisis” or “no crisis”, and not in terms of their severity. There are several important policy implications of these results. First, openness to foreign bank entry, especially in the form of brick and mortar operations, should be pursued as a general policy objective. However, this openness should not be without qualifications. Regulatory bodies should be careful and deliberate with respect to direct cross-border lending, which has a less certain effect on stability, at least until further studies on this topic are conducted. The second policy implication has to do with the credit growth results. Because high credit growth is strongly associated with subsequent crisis, monetary policy should be conducted with an eye toward the speed of credit expansion. If central banks actively monitor and address lending booms in order to slow the pace of credit growth, some future crises might be avoided or alleviated. For example, Gavin and Hausman (1998) suggest that central bank adjustment of bank reserve or liquidity requirements might be beneficial during 13 Latin American credit booms, in order to oblige banks to expand their loan portfolios more gradually. We conclude that foreign banks have the potential of significantly improving domestic banking stability and lessening the chance of a banking crisis, especially in the form of “brick and mortar” operations within the country. More research should be done on the effect of direct cross-border lending, so that its repercussions can be more definitively determined. 6 Appendix: Data Description and Sources Local Foreign is defined as the ratio of local currency claims of reporting banks on local residents to domestic credit provided by banking sector; while International Foreign is defined as the ratio of total claims of international reporting banks to domestic credit to private sector. The measure for Credit Growth is given by the growth of domestic credit to the private sector as a percentage of GDP. GDP Growth, Inflation, and Depreciation are given by the percent changes per year of the respective variables. Liquidity is given by the ratio of bank liquid reserves to bank assets, while M2/Reserves is given by the ratio of M2 to gross international reserves. All data were obtained from the World Bank Development Indicators and the International Financial Statistics, except for the Foreign Bank Presence Measures, which stem from bank reports to the BIS. 14 References [1] Barth, J., G. Caprio Jr. and R. Levine (2001). "Banking Systems Around the Globe: Do Regulation and Ownership Affect Performance and Stability?", in Prudential Supervision: What Works and What Doesn’t, F. S. Mishkin (ed.), Chicago: University of Chicago Press, pp. 31-88. [2] Buyukkarabacak, B. and N. Valev (2006). "Credit Expansions and Firm Credit: The Roles of Household and Firm Credit", Andrew Young School of Policy Studies Research Paper, No. 06-55. [3] Caprio Jr., G., and P. Honohan (2003). 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"The Role of the State in Financial Markets", in Proceedings of the World Bank Annual Conference on Development Economics, pp. 19—52. 17 Table 1: Episodes of Systemic Banking Crises in Latin America and the Caribbean since 1982 Country Start date(s) Argentina 1989, 1995, 2001 Bolivia 1986, 1994 Brazil 1990, 1994 Colombia 1982 Ecuador 1996, 1998 El Salvador 1989 Jamaica 1994, 1995 Mexico 1994 Paraguay 1995 Peru 1983 Uruguay 2002 Venezuela 1994 Source: Caprio and Klingebiel 2003. 18 Figure 1: Local Currency Claims of BIS reporting banks on Latin American residents (proportion of entire region’s domestic credit provided by banking sector) 0.35 0.3 0.25 0.2 0.15 0.1 0.05 0 1983 1985 1987 1989 1991 1993 1995 Source: Own computations based on BIS and World Bank data 19 1997 1999 2001 2003 Table 2: Local Foreign Bank Measure (Country-specific fixed effects) Local Foreign (1) (2) (3) -17.915 (0.03) -17.388 (0.04) -16.685 (0.04) Local Foreign (IV) (4) (5) (6) -20.378 (0.03) -19.316 (0.04) -19.097 (0.04) Credit Growth t-1 1.193 (0.41) 1.000 (0.59) 0.946 (0.55) 0.676 (0.64) -0.030 (0.98) 0.091 (0.96) Credit Growth t-2 5.162 (0.01) 5.066 (0.00) 4.887 (0.01) 4.557 (0.01) 4.227 (0.02) 4.083 (0.02) GDP Growth -0.230 (0.01) -0.225 (0.01) -0.213 (0.01) -0.241 (0.00) -0.228 (0.00) -0.217 (0.01) Trend 0.159 (0.10) 0.161 (0.09) 0.166 (0.09) 0.235 (0.05) 0.244 (0.04) 0.247 (0.04) 0.017 (0.82) Inflation 0.048 (0.61) Depreciation Number of observations Chi-statistic 0.057 (0.50) 0.086 (0.48) 192 192 192 176 176 176 25.86 (0.00) 25.91 (0.00) 26.26 (0.00) 22.91 (0.00) 23.43 (0.00) 23.89 (0.00) Banking crisis dummy takes the value one if there is a crisis and zero otherwise. p-values are in parentheses. 20 Table 3: International Foreign Bank Measure (Country-specific fixed effects) International Foreign (1) (2) (3) -1.433 (0.51) -1.420 (0.52) -1.379 (0.53) International Foreign (IV) (4) (5) (6) 19.767 (0.55) 18.838 (0.58) 17.511 (0.60) Credit Growth t-1 1.505 (0.28) 1.437 (0.31) 1.514 (0.28) 1.734 (0.18) 1.706 (0.20) 1.747 (0.18) Credit Growth t-2 3.924 (0.01) 3.906 (0.01) 3.905 (0.01) 4.015 (0.00) 4.009 (0.00) 4.001 (0.00) GDP Growth -0.224 (0.00) -0.222 (0.00) -0.218 (0.00) -0.205 (0.01) -0.214 (0.01) -0.200 (0.01) Trend 0.008 (0.90) 0.012 (0.85) 0.014 (0.82) -0.451 (0.54) -0.428 (0.57) -0.394 (0.60) 0.008 (0.78) Inflation 0.012 (0.60) Depreciation Number of observations Chi-statistic 0.004 (0.90) 0.009 (0.68) 195 195 195 192 192 192 16.99 (0.00) 17.05 (0.00) 17.20 (0.00) 16.94 (0.00) 16.95 (0.00) 17.08 (0.00) Banking crisis dummy takes the value one if there is a crisis and zero otherwise. p-values are in parentheses. 21 Table 4: Local Foreign Bank Measure (Country-specific fixed effects) Excluding years of ongoing crisis Local Foreign (1) (2) (3) -20.139 (0.01) -19.173 (0.01) -19.222 (0.01) Local Foreign (IV) (4) (5) (6) -23.581 (0.01) -22.347 (0.01) -22.318 (0.01) Credit Growth t-1 0.888 (0.68) 0.519 (0.82) 0.605 (0.79) -0.215 (0.91) -0.904 (0.69) -0.716 (0.75) Credit Growth t-2 5.934 (0.01) 5.537 (0.01) 5.618 (0.01) 5.413 (0.01) 4.731 (0.04) 4.880 (0.03) GDP Growth -0.385 (0.00) -0.374 (0.00) -0.371 (0.00) -0.410 (0.00) -0.391 (0.00) -0.387 (0.00) Trend 0.211 (0.04) 0.221 (0.03) 0.219 (0.03) 0.317 (0.01) 0.330 (0.01) 0.327 (0.01) 0.089 (0.60) Inflation 0.075 (0.65) Depreciation Number of observations Chi-statistic 0.131 (0.42) 0.109 (0.49) 161 161 161 148 148 148 32.28 (0.00) 32.64 (0.00) 32.56 (0.00) 30.50 (0.00) 31.39 (0.00) 31.15 (0.00) Banking crisis dummy takes the value one if there is a crisis and zero otherwise (excluding the years of ongoing crisis). p-values are in parentheses. 22 Table 5: International Foreign Bank Measure (Country-specific fixed effects) Excluding years of ongoing crisis International Foreign (1) (2) (3) 0.596 (0.83) 0.593 (0.83) 0.616 (0.83) International Foreign (IV) (4) (5) (6) 45.056 (0.28) 44.600 (0.28) 44.533 (0.29) Credit Growth t-1 2.441 (0.23) 2.485 (0.22) 2.509 (0.22) 3.088 (0.15) 3.088 (0.15) 3.095 (0.15) Credit Growth t-2 4.440 (0.01) 4.412 (0.01) 4.413 (0.01) 4.133 (0.01) 4.133 (0.01) 4.132 (0.01) GDP Growth -0.311 (0.00) -0.308 (0.00) -0.306 (0.00) -0.285 (0.00) -0.285 (0.00) -0.285 (0.00) Trend 0.005 (0.93) 0.010 (0.88) 0.010 (0.88) -0.977 (0.29) -0.977 (0.29) -0.976 (0.29) 0.008 (0.77) Inflation 0.007 (0.75) Depreciation Number of observations Chi-statistic 0.003 (0.92) 0.003 (0.91) 163 163 163 160 160 160 20.61 (0.00) 20.68 (0.00) 20.69 (0.00) 21.86 (0.00) 21.86 (0.00) 21.87 (0.00) Banking crisis dummy takes the value one if there is a crisis and zero otherwise (excluding the years of ongoing crisis). p-values are in parentheses. 23