Capital flows, degree of openness and macroeconomic volatility.
Chakraborty, Debasish ; Boasson, Vigdis
Abstract
This paper examines the effects of capital inflow on the volatility
of output and price using panel data. The major contribution of the
paper lies in incorporating the effects of degree of financial openness
in analyzing the effects of capital flows on macroeconomic volatility.
Specifically the paper investigates whether the degree of financial
openness influences the impact of capital flows on macroeconomic
volatility. Our model uses the KOF globalization index as a proxy for
openness. Our results show that as financial openness increases, the
capital inflow has less impact on macroeconomic volatility. This could
be due to an increase in the proportion of direct foreign investment
compared to portfolio investment and with a highly integrated banking
sector the possibilities of a currency and maturity mismatch are lower.
JEL Codes F36 F62 and F65
Keywords: Economic Globalization, Economic Integration, Capital
Flows, Financial Liberalization
1. INTRODUCTION
There is a great deal of debate among economists about the effects
of international capital inflow on economic growth and stability. IMF and the World Bank spearheaded the arguments that developing countries
need to open up their capital account in an orderly, deliberate and
sustainable fashion in order to accelerate economic growth. They also
argue that international capital flows also help with macroeconomic
stability. The higher growth results from efficient allocation of
resources and the reduction of macroeconomic volatility came from the
ability to smoothly borrow and lend internationally in response to
domestic economic conditions. However, economic data suggests that
international capital flows also increases volatility of output,
consumption and exchange rates. So often instead of increasing
macroeconomic stability (as argued by the IMF and the World Bank),
capital flows can actually increase macroeconomic instability, at least
in the short run. This tradeoff between growth and volatility has led to
intense debates among policy planners about the efficiency of opening up
of the capital account.
This paper addresses this debate by investigating the effects of
capital inflow on the volatility of output and price using panel data.
The major contribution of the paper lies in incorporating the effects of
degree of financial openness in analyzing the effects of capital flows
on macroeconomic volatility. Specifically the paper investigates whether
the degree of financial openness influences the impact of capital flows
on macroeconomic volatility. Our model uses the KOF globalization index
as a proxy for openness. The KOF globalization index is a weighted
average economic, political and social openness.
The paper is organized in the following manner. Section 2 provides
a survey of literature on the effects of capital flows on economic
growth and volatility, section 3 discusses the data and methodology,
section 4 deals with the empirical analysis and section provides the
summary and the conclusions of this paper. The paper concludes that as
financial openness increases, the capital inflow has less impact on
macroeconomic volatility. This could be due to an increase in the
proportion of direct foreign investment compared to portfolio investment
and with a highly integrated banking sector the possibilities of a
currency and maturity mismatch are lower.
2. SURVEY OF LITERATURE
It has been argued that financial openness helps augment the level
of domestic resources that are crucially needed for economic growth.
However, it is also true that financial openness and the surge in
capital inflow contributes to macroeconomic volatility, especially in
developing and emerging economies. The most common effect of a surge in
capital inflow is appreciation in the exchange rate. Under a flexible
exchange rate this appreciation comes via the appreciation of the
nominal exchange rate. Under fixed exchange rate, a surge in capital
flows lead to an expansion of money supply and liquidity, which results
in an increase in aggregate demand, increase in the price of
non-tradable goods, and inflation. Thus the surge in financial flows has
the potential of derailing the economic reform process of the type
recommended by the IMF and the World Bank.
An increase in capital inflow and the consequent surplus in the
capital account are often matched by a simultaneous deficit in the
current account. This deficit in current account could be due to
increase in private consumption (as in Latin America) or private
investment (as in Asia). So a surge in capital inflow, in addition to
its impact on exchange rate and inflation, thus, has some direct effect
on consumption, investment and output. The impact on volatility depends
largely on the composition of the capital flows. It has been argued that
the volatility will be less pronounced if the proportion of foreign
direct investment is higher than portfolio investment. Macroeconomic
volatility resulting from surge in capital inflow also increases if the
possibility of currency mismatch (bank liabilities denominated in
foreign currencies and bank assets denominated in local currency) and
maturity mismatch (bank liability is mainly short term in nature and
bank lending is long term in nature) higher.
Since capital flows impacts both economic growth and macroeconomic
stability, it is critical to weigh in the effects on each one of them
before adopting a formal policy of opening up the economy. This section
provides a brief summary of the effects of capital flows on economic
growth. However, the survey of literature on the effects of capital
flows on volatility is much more extensive, since that is the thrust of
this paper.
2a. Effect of Capital Account Liberalization on Economic Growth
There is mixed evidence on the effects of capital account
liberalization on economic growth. Licchetta (2006) summarizes the
findings of fifteen recent studies on the effects of capital account
liberalization on economic growth as shown in Table 1 as follows:
Table 1
Capital Account Liberalization and Economic Growth
# of
Study countries Years
Alesina, Grilli and Ferretti (1994) 20 1950-89
Grilli and Ferretti(1995) 61 1966-89
Quinn (1997) 58 1975-89
Kraay (1998) 117 1985-1997
Rodrik (1998) 95 1975-89
Klein and Olivei (2000) Up to 92 1986-95
Chanda (2001) 116 1976-89
Arteta, Eichengreen, Wypolosz (2001) 51-59 1973-92
Bekaert, Harvey, Lundblad (2001) 30 1981-97
Edwards (2001) 62 1980s
O'Donnel 94 1971-94
IMF 38 1980-99
Reisen and Soto(2001) 44 1986-1997
Edison, Levine, Ricci, Slok (2002a) Up to 89 1973-1995
Edison, Levine, Ricci, Slok (2002b) 57 1980-2000
Study Effecton Growth
Alesina, Grilli and Ferretti (1994) No effect
Grilli and Ferretti(1995) No effect
Quinn (1997) Positive
Kraay (1998) No effect/mixed
Rodrik (1998) No effect
Klein and Olivei (2000) Mixed
Chanda (2001) Mixed
Arteta, Eichengreen, Wypolosz (2001) Mixed
Bekaert, Harvey, Lundblad (2001) Positive
Edwards (2001) No effects on poor
countries
O'Donnel No effect/mixed
IMF Positive/not significant
Reisen and Soto(2001) Mixed
Edison, Levine, Ricci, Slok (2002a) Mixed
Edison, Levine, Ricci, Slok (2002b) No effect
Source: Prasad et al. (2003), IMF (2001) and Edison et al. (2002a):
reproduced from Licchetta (2006).
2b. Effects of Capital Account Liberalization on Macroeconomic
Volatility
The effect of capital account liberalization on macroeconomic
volatility is similarly mixed. Mendoza (1994) uses a stochastic dynamic
business cycle model and finds very little connections between financial
openness and volatility of output and consumption. He however finds that
if the shocks are big and prolonged than output and consumption
volatility increases with degree of financial openness. Baxter and
Crucini (1995) find that with increased financial openness output
volatility increases but consumption volatility falls (both consumption
and relative consumption volatility). Possible reason for these
differences can be attributed to wealth effect on consumption and the
interaction of these assets on the implications of these effects on the
risks associated with different assets structures.
Sutherland (1996), Senay (1998) and Buch, Dopke and Pierdzioch
(2002) uses dynamic stochastic stick-price models and all these studies
conclude that the impact of financial openness on macroeconomic
volatility depends on some exogenous shocks. In the case of monetary
shocks volatility of output increases; In the case of fiscal shocks
volatility of output decreases. In the case of monetary shocks
volatility of consumption decreases, while in the case of fiscal shocks
the volatility of consumption increases.
The impact of financial openness on Macroeconomic volatility can be
also explained by the structural conditions of the economy. If a country
embarking upon financial openness has a limited diversification of
exports and imports, then financial openness could contribute to
macroeconomic volatility through its impact on the terms of trade and
foreign demand shocks. Kose (2002) examines these effects by inspecting
the effects on the terms of trade and Senhadji (1998) examines the role
played by foreign demand shocks.
Countries where the level of financial openness is not that deep
and countries which are highly indebted often can experience capital
flow reversal which could lead to fierce macroeconomic volatility. Also
in these countries, changes in the world interest rate could trigger
serious macroeconomic volatility. Aghion, Banerjee, and Piketty (1999)
and Caballero and Krishnamurthy (2001) shows the relationship between
financial openness and macroeconomic volatility by focusing on countries
with not so developed financial markets and countries who are highly
indebted.
Financial openness seems to have more impact on small countries
than large countries. Head (1995) and Crucini (1997) made the case that
productivity shifts in large countries contribute to macroeconomic
volatility in small countries. Kose and Prasad (2002) financial openness
contributes to macroeconomic volatility much more in small countries
(population below 1.5 million) than other developing countries.
Kaminsky and Reinhart (1999) and Glick and Hutchinson (1999) showed
that countries starting financial liberalization experienced high
volatility in output and consumption due to sudden loss of access to
global financial markets. Mendoza (2002) and Arellano and Mendoza (2002)
however, shows that sudden stop in access to financial markets did not
cause any sever macroeconomic volatility.
Razin and Rose (1994) uses cross section data to estimate
volatility and found no significant link between financial openness and
macroeconomic volatility. They also argue that financial openness seems
to amplify monetary shocks and dampens fiscal shock.
Easterly, Islam and Stiglitz (2004) uses 2 periods panel OLS and IV
method and concludes that neither the level nor the volatility of
private capital flows have any significant impact on output growth
volatility. Koseand Plummer (2003) use a sample of 76 countries over a
period of 1960-1999. He uses two indicators of financial openness: (a)
dummy variable for capital account restrictions and (b) private capital
flows. Financial openness is not significant in explaining output and
consumption volatilities. Financial openness has a significant and
non-linear impact on relative consumption volatilities (ratio of
consumption to output volatilities).
Eozenou Patrick (2008) uses GMM -IV panel estimation method as
proposed by Arellano and Bover (1995) and Blundell and Bond (1998) to
estimate the following two equations:
[[sigma].sub.i,j,t] = [sigma][[alpha].sub.i,j,t-1] +
[[beta].sub.1][Q'.sub.i,t] + [[beta].sub.2][FD.sub.i,t] +
[[eta].sub.i] + [[epsilon].sub.it,t] (2)
[[sigma].sub.i,j,t] = [sigma][[alpha].sub.i,j,t-1] +
[[beta].sub.1][Q'.sub.i,t] + [[beta].sub.2][FD.sub.i,t] +
[[beta].sub.3][FI.sub.i,t] + [[beta].sub.4] ([FD.sub.i,t] *[FI.sub.i,t])
+ [[eta].sub.i] + [[epsilon].sub.it,t] (3)
Where j = Y, C and C+G;
[Q'.sub.i,t] are a set of control variable;
[FD.sub.i,t] is a measure of financial development;
[FI.sub.i,t] is a measure of financial openness.
They concluded that lagged dependent variable has significant and
positive effects on volatility in terms of trade volatility and share of
agricultural sector on GDP (all control variables). It also has a
positive impact on output growth volatility. However, these terms have
no impact on consumption growth volatility. They found evidence to show
that financial openness has a positive impact on output growth
volatility up to a certain level of financial development, but the
coefficient is not statistically significant. The marginal impact of
financial development on consumption is negative for both private and
total consumption growth volatility. The marginal impact of financial
openness on consumption is positive for both private and total
consumption growth volatility. Both these coefficients are not
significant. So taken independently, each of these two variables has no
impact on consumption growth volatility. However inclusion of the
interaction term matters. [B.sub.3] is positive and significant.
[B.sub.4] is a significant negative coefficient. This suggests that as
financial development increases, the positive impact of financial
openness on consumption volatility becomes weaker. Financial integration
has a positive impact on consumption volatility when financial
development is low, but when financial system is strong enough, then
financial integration lowers consumption volatility. This paper
concludes that the impact of financial development on consumption
depends upon the level of financial development.
3. METHODOLOGY AND DATA
Severalempirical concerns help determine the choice of our
econometric model: (i) the potential endogeneity of the domestic
savings; (ii) the dynamic relationship between domestic savings and
investment as both are impacted by the prior values of each other; and
(iii) unobserved country- specific effects. (1) This leads us to specify
the dynamic panel GMM estimator proposed by Arellano and Bond (1991) to
overcome these potential issues. According to this technique, the model
is transformed in two-step GMM estimator to eliminate the fixed effects
to derive unbiased and consistent estimates. Under this transformation,
the lagged values of the endogenous variables are used as suitable
instruments to overcome the potential endogeneity problem.
For the measure of volatility, we use the measure employed by
Rodrik (1998) and Iverson (2001). Thus volatility is measured by
standard deviation of the concerned economic aggregate. To measure
output volatility we use the standard deviation of real GDP and to
measure price volatility we use the GDP deflator. In order to maintain
sufficient number of data for empirical analysis we use the five year
period standard deviation.
We estimate the following two equations in the paper:
Output Volatility
[MATHEMATICAL EXPRESSION NOT REPRODUCIBLE IN ASCII] (4)
Where [[sigma].sub.GDP] is the five-year standard deviation of real
GDP;
KF is the capital flow;
G is the globalization index.
Price Volatility
[MATHEMATICAL EXPRESSION NOT REPRODUCIBLE IN ASCII] (5)
Where [[sigma].sub.PR] is the five-year standard deviation of GDP
deflator;
KF is the capital flow;
G is the globalization index.
Panel Data
We collected macroeconomic indicator data on real GDP, GDP
deflators, and CPI across 208 countries for the time-series of 1966-2009
from the World Bank's database called "World Databank".
We computed five-year moving standard deviations on real GDP growth
rates, GDP deflators, and CPI for the period of 1970 -2009. We then
matched our volatility variables with the 2012 KOF Index of
Globalization across 208 countries for the time-series of 1970-2009.
This yielded a panel dataset with 8320 observations. KOF Index of
Globalization was introduced in 2002 (Dreher, 2006) and is updated and
described in detail in Dreher, Gaston and Martens (2008).
Table 2 presents the summary statistics on the variables of our
panel study. The variable on capital flows includes data on trade, FDI and portfolio investment. The sources of the data are from the World
Bank, UNUTAD, and IMF. Specifically, trade data are the sum of a
country's exports and imports; FDI is a country's net flows of
inflows and outflows of FDI; portfolio investment is the sum of a
country's stock of assets and liabilities. All these variables are
normalized by GDP. The entire cross-sectional and time-series sample has
a mean capital flows of 51.6 per cent of GDP with a standard deviation
of 22% and coefficient of variations (CV) 0.43.
The KOF globalization index measures the three dimensions of
globalization on economic, social and political globalization. The
higher value of the globalization index indicates a higher level of a
country's openness. The index calculated on a yearly basis. The
globalization index variable has a mean of 45.3, a standard deviation of
17.6 and coefficient of variation of 0.39.
We measure macroeconomic volatilities by computing the five-year
moving standard deviations of a country's real GDP annual growth
rates, GDP deflator, and consumer price index (CPI). The average
standard deviation for the GDP growth rates, and GDP deflator and CPI
are approximately 4%, 66%, and 6% respectively.
4. EMPIRICAL RESULTS
For empirical econometric analysis, we estimate several panel
models for variability in output (as measured by standard deviation of
GDP growth) and variability in price (as measured by standard deviation
in GDP deflator). Table 3, 4 and 5 summarize the results of the effects
of capital inflow on variability in output and Table 6 summarizes the
effects of capital inflow on price variability. Table 3 reports the
results of the panel model with fixed effects and Arellano robust
standard errors.
The lagged dependent variable is positively correlated with the
volatility on GDP growth and the result is statistically significant at
1 per cent level. Even though capital flows is negatively correlated
with the GDP volatility, the result is not statistically significant.
However, the globalization index which is the proxy for a country's
openness is negatively correlated with the GDP volatility and the result
is statistically significant at 1 per cent level. This result indicates
that the higher the level of openness, the lower level of the volatility
on GDP growth. In other words, if a country increases its level of
globalization or openness, it can help reduce its volatility on GDP
growth and stabilize its economy. More interestingly, the interaction
between capital flows and globalization is positively correlated with
the volatility on GDP growth and this result is statistically
significant at 1 per cent level. This suggests that as the level of
capital flow increases, it increases the volatility of GDP growth when
the country's level of openness is low. This indicates that the
level of openness is low, the beneficial effects of globalization is not
large enough to offset the adverse effects of capital flows on
volatility of GDP growth. Thus, the impact of capital flows on GDP
growth volatility depends on the level of globalization or financial
openness.
The lagged dependent variable is positively correlated with the
volatility on GDP growth and the result is statistically significant at
1 per cent level. Capital flows is positively correlated with the GDP
volatility; the result is statistically significant at the 5% level.
However, the globalization index which is the proxy for a country's
openness is negatively correlated with the GDP volatility and the result
is statistically significant at 5 per cent level. This result also
indicates that the higher the level of openness, the lower level of the
volatility on GDP growth. In other words, if a country increases its
level of globalization or openness, it can help reduce its volatility on
GDP growth and stabilize its economy. This estimation model also
suggests that the impact of capital flows on GDP growth volatility
depends on the level of globalization or financial openness.
With a pooled OLS estimation (Table 5), both the capital flow
coefficient and the interaction term between the capital flow and
globalization index are statistically insignificant. The globalization
index coefficient has the right sign and is also statistically
significant at 1% level.
The effect of capital flows on the price volatility is quite the
opposite. It is clear from Table 6 that capital flow coefficient has the
right sign but is statistically not significant. The globalization term
is significant at the 10% level but has a positive sign. This indicates
that higher the level of openness, greater the price volatility.
However, the interaction term is statistically significant and has a
negative sign, indicating that increased capital flows would increase
price volatility if the level of openness is high.
5. SUMMARY
The effects of capital flows on output volatility are nearly
identical irrespective of the estimation techniques used for estimation.
Increase in capital flows generally increases output volatility; whereas
output volatility is reduced more open the economy. For the same level
of capital flows generally the volatility is higher more open the
economy. However volatility in price is increased with globalization and
for the same level of capital inflows, price volatility is reduced as
the level of openness increases.
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DEBASISH CHAKRABORTY * AND VIGDIS BOASSON, College of Business
Administration, Central Michigan University, Mt Pleasant, MI 48859
Table 2
Summary Statistics, using the Observations for 208 Cross-sectional
Countries over 40 periods (1970-2009)
Variable Mean Median Min Max
capital flows 51.604 50.531 4.632 100.000
globalization index 45.340 42.352 12.216 92.836
St. Dev of GDP growth 3.97 2.85 0.00 55.49
St. Dev of GDP deflator 66.26 4.73 0.00 27767.50
St. Dev of CPI 5.81 3.87 0.00 775.47
Variable Std. Dev. C. V.
capital flows 22.136 0.429
globalization index 17.591 0.388
St. Dev of GDP growth 3.944 0.993
St. Dev of GDP deflator 1003.220 15.141
St. Dev of CPI 18.198 3.134
Table 3
Panel Model with Fixed-effects for 208 Countries over the Period
of 1970-2009 (robust (HAC) standard errors)
Dependent variable: SD_GDPg
Coeff S.E. t-ratio p-value
constant 2.224 0.304 7.306 <0.00001 ***
capital flows -0.003 0.008 -0.381 0.704
globalization index -0.041 0.006 -6.852 <0.00001 ***
cap flows * glob 0.000 0.000 2.915 0.004 ***
SD_GDPg_1 0.789 0.008 99.932 <0.00001 ***
Table 4
Dynamic Panel Model with Two-Step GMM Estimator for 208 Countries
over the Period of 1970-2009
Dependent variable: SD_GDPg
Coeff S.E. z
constant 0.87118 0.1706 5.1036
SD_GDPg (-1) 0.84319 0.01878 44.9049
capital flows 0.00686 0.00329 2.0835
globalization index -0.02125 0.01080 -1.9669
Cap flow*glob 0.00046 0.00028 1.6626
p-value
constant <0.00001 **
SD_GDPg (-1) <0.00001 ***
capital flows 0.03721 *
globalization index 0.04919 **
Cap flow*glob 0.09640
Table 5
Pooled OLS, using 5417 Observations
Included 172 cross-sectional units
Dependent variable: SD_GDPg
Coefficient Std. Error t-ratio
constant 1.02061 0.170303 5.9929
Capflow*glob 4.64452e-05 6.09103e-05 0.7625
Capital flows 0.00403009 0.00299558 1.3453
Global index -0.016056 0.00405876 -3.9559
SD_GDPg_1 0.837506 0.00642824 130.2855
p-value
constant <0.00001 ***
Capflow*glob 0.44578
Capital flows 0.17857
Global index 0.00008 ***
SD_GDPg_1 <0.00001 ***
Table 6
2-step Dynamic Panel GMM, using 5456 Observations
Included 208 cross-sectional countries
Time-series length: 1979-2009
Dependent variable: Price Volatility=SD_GDPdeflator
Coeff S.E. z
constant -20.0155 9.74967 -2.0529
SD_GDPdefl(-1) 1.03969 0.00971279 107.0438
Capflow* glob -0.0091765 0.00463033 -1.9818
capitalflows 0.371151 0.263914 1.4063
Globalization index 0.612927 0.37188 1.6482
p-value
constant 0.04008 **
SD_GDPdefl(-1) <0.00001 ***
Capflow* glob 0.04750 **
capitalflows 0.15962
Globalization index 0.09931 *