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Exports and economic growth in India: cointegration, causality and error-correction modeling: a note.

Abstract

This paper uses stationarity, cointegration, and Granger causality tests to analyze the relationship between exports and economic growth in India over the preliberalization period 1960-92. The analysis is conducted within a rigorous econometric framework that accounts for optimal lag selection and simultaneity bias. We find strong support for uni-directional causality from exports to economic growth using Granger causality regressions based on stationary variables, with and without an error-correction term. Unlike previous studies which ignore such fundamental issues as export-economic growth simultaneity, we use a Seemingly Unrelated Regression (SUR) procedure to account for possible simultaneity bias between exports and economic growth.

Introduction

The causal relationship between exports and economic growth pertains to a fundamental question in economics what factors determine economic growth? From the viewpoint of economic policy, this is an important issue because if exports cause growth [export led growth (ELG) hypothesis], export promotion through policies such as export subsidies or exchange rate depreciation will increase growth. The substance of the neoclassical arguments underlying the export led growth hypothesis is that competition in international markets promotes scale economies and increases efficiency by concentrating resources in sectors in which the country has a comparative advantage. These positive externalities promote economic growth [see, for instance, Bhagwati (1978), Balassa (1978), Krueger (1978), Feder (1982)]. The reverse side of this argument that economic growth promotes export growth relies on the notion that gains in productivity give rise to comparative advantages in certain sectors that lead naturally to export growth. Also, countries with high growth rates and relatively low absorption rates must necessarily export the excess output.

India is an interesting case study of the export economic growth relationship. It is difficult from the Indian experience to a priori assess the nature of this causal relationship. The trade sector constitutes a small section of the Indian economy and this seems to indicate a minor role for exports in economic development. However, it is important to recognize that the size of the export sector in India does not by itself exclude the possibility of export-led growth. Little, et al. (1993; p. 118) in a discussion of the development experience of LDCs point out that "The relationship between export performance and growth does not arise merely because exports are part of GDP. Except for a handful of countries, the value of exports was not a very high proportion of GDP even in 1988.... In the main, it appears that rapid export growth relieves a country in balance of payments difficulties from having to compress imports by import restrictions or deflationary action. It permits a more liberal trade regime with all the benefits associated with the exploitation of comparative advantage..... It also makes a country more creditworthy, while relief from a dominating concern with debt and the balance of payments permits authorities to pursue economic reforms outside the field of trade and payments".

Up to the 1960s, India had followed an import substitution policy. However, the failure of import substitution as a viable industrial policy and the rapid escalation of import bills and balance of payments deficits in the late 1960s forced India to shift to an export oriented strategy. Recent economic reforms in India have largely accentuated this export orientation.

A large empirical literature has re-examined the ELG hypothesis with mixed findings [see, for instance, Jung and Marshall (1985), Chow (1987), Hsiao (1987), Kwan and Cotsomitis (1991), Ahmad and Kwan (1991), Marin (1992), Oxley (1993), Fung et aI. (1994), Shan and Sun (1998) and Moosa (1999)]. The ELG hypothesis, as it pertains to India, has been examined by Nandi and Biswas (1991), Sharma and Dhakal (1994), Mallick (1996), and more recently by Dhawan and Biswal (1999), Nidugala (2000), and Anwer and Sampath (2001). The empirical evidence offered by these papers is, however, mixed. Dhawan and Biswal (1999) examine the period between 1961-93 and find that growth in GDP causes growth in exports while causality from exports to GDP appears to be a short run phenomenon. Nidugala (2000) finds that exports had a crucial role in influencing GDP growth in the 1980s. Anwer and Sampath (2000) examine the export-economic growth nexus for a wide cross section of developing countries over the 1960-92 period. They find that exports and economic growth in India are cointegrated but do not find any strong evidence of causality from exports to economic growth or vice versa.

In much of the ELG literature as it pertains to India, there is little recognition of the importance of issues such as stationarity and cointegration in empirical testing. Nandi and Biswas (1991) and Sharma and Dhakal (1994) offer some evidence of the ELG hypothesis for India but the empirical evidence offered by both papers is unreliable. Nandi and Biswas (1991) do not test for stationarity and conduct Sims causality tests on the levels of the income and export variables. Given that the levels of the income and export variables are usually non stationary, Nandi and Biswas' results are unreliable. Sharma and Dhakal (1994) conclude that the income and export series for India are non stationary using the Phillips Perron test. They test for causality but do not test for cointegration. However, the correct application of Granger tests requires the identification of a possible cointegrating relationship. If the levels of the export and income series have a unit root (i.e. the series are non stationary) and are cointegrated, the appropriate Granger causality tests must be constructed either on levels or on the stationary differenced series with an error correction term derived from the cointegrating relationship. Our paper corrects problems in previous empirical studies on the ELG hypothesis in India by not only adjusting for issues such as stationarity, cointegration and error-correction but also applying these tests within the context of a more rigorous and sophisticated econometric framework. For instance, evidence of cointegration between exports and economic growth by itself implies the existence of at least uni-directional causality. Another important aspect of causality testing involves determining the optimal number of lags in the Granger regressions. These lags are usually chosen in an ad-hoe manner resulting in a mis-specification of the autoregressive process. Akaike's Final Prediction Error (FPE) criterion provides a robust method of determining the order of the bi-variate autoregressive process. Combining the FPE method with the Granger definition of causality provides an econometrically rigorous method of testing causality.

One further issue that is almost invariably ignored but is fundamental to any study of the ELG hypothesis is the simultaneity problem. Since exports and economic growth are jointly determined, application of single equation ordinary least squares (OLS) will result in both inconsistent and inefficient estimates. The simultaneity problem can, however, be eliminated by using the SUR (Seemingly Unrelated Regression) procedure--a procedure that we apply in our paper.

Our paper thus overcomes some of the shortcomings of previous empirical studies on the ELG hypothesis in India by adjusting for stationarity, cointegration and error correction within a more robust econometric framework than used in other similar work in this area.

Econometric Formulation

In this section, we discuss the methods of testing for stationarity, cointegration and causality. Our first objective is to determine the time series properties of real exports and real GDP before testing for the presence of causal relationship between these variables.

A variable [x.sub.t] is said to be integrated of order d, I(d), if it becomes integrated of order 0, I(0) (i.e., stationary) after being differenced d times (Engle and Granger, 1987). The order of integration of [x.sub.t] can be tested using the following regression:

[MATHEMATICAL EXPRESSION NOT REPRODUCIBLE IN ASCII] (1)

The test statistics [??]/[sigma]([??]) is referred to as the Dickey-Fuller (DF) test when [[delta].sub.i] = 0, [[for all].sub.i] and is referred to as the Augmented Dickey-Fuller (ADF) test when [[delta].sub.i] [not equal to] 0, [[for all].sub.i]. The optimal lag length, p, is chosen such that the error term et is white noise (1). The optimal lag length can be determined using the Ljung-Box statistic (Ljung and Box, 1978). If [beta] is negative and significantly different from zero, the null hypothesis of a unit root ([H.sub.0]: [beta] = 0) or nonstationarity is rejected. Failure to reject the null implies that [x.sub.t] is non-stationary and has a unit root. Under the null hypothesis, the DF test statistic does not have a standard t distribution. However, the critical values for this test are tabulated by Engle and Yoo (1987).

Now consider two variables [x.sub.t] and [y.sub.t], both of which are integrated of order d. The series [x.sub.t] and [y.sub.t] are said to be cointegrated, if there exists the linear combination, [z.sub.t] = [x.sub.t] - [alpha][y.sub.t]. such that [z.sub.t] is integrated of order d-b, I(d-b), b>0 (see Engle and Granger, 1987). The cointegrating regression is then given by:

[y.sub.t] = [alpha] + [[beta][x.sub.t] + [z.sub.t] (2)

If [x.sub.t] and [y.sub.t] are both integrated of order one, I(1) and the error term [z.sub.t] in (2) is stationary then [x.sub.t] and [y.sub.t] are "cointegrated". The null hypothesis in this test [z.sub.t] is that is nonstationary (i.e. non-cointegration). There are two fundamental implications of cointegration. First, cointegration among two variables can be interpreted as the presence of long-run equilibrium relationship between the variables and as a result they will not drift far apart in the long run. Second, cointegration between [x.sub.t] and [y.sub.t] by itself implies the existence of at least, unidirectional Granger causality between the two variables.

The Granger Representation Theorem states that if [x.sub.t] and [y.sub.t] are I(1) and cointegrated, there exists an error-correction model of the form:

[MATHEMATICAL EXPRESSION NOT REPRODUCIBLE IN ASCII] (3)

[MATHEMATICAL EXPRESSION NOT REPRODUCIBLE IN ASCII] (4)

where [z.sub.t-1] and [z.sub.t-1], are the error-correction terms that represent the extent to which [x.sub.t] and [y.sub.t] deviate from their equilibrium values (2). This result has important implications for testing the export-led growth hypothesis. According to the Granger Representation Theorem, if two variables are I(1) and cointegrated, then the VAR can be estimated either in levels or in first differences with an error-correction term included. On the other hand, if two variables are I(1) but not cointegrated, then the vector autoregressive (VAR) model must be constructed in terms of stationary variables (i.e., first differences).

A. Empirical Results

To test the ELG hypothesis in India, we use the log of real exports (LREXP) and the log of real GDP (LRGDP). Nominal exports and nominal GDP were deflated by an export price index and a GDP deflator series. The data consists of annual observations between 1960-92 collected from various issues of International Financial Statistics (IFS). We focus on the 1960-92 period because the period after 1992 may be structurally different in view of the liberalization reforms undertaken by the Indian government.

Before testing the order of integration of LREXP and LRGDP, we need to determine the optimal value of p required to ensure that the error term in equation (1) is white noise. This can be determined through the Box-Pierce Q statistic or the Ljung-Box statistic. We choose to use the Ljung-Box (LB)statistic because of its better small sample properties. The LB statistic is given by (Ljung and Box, 1978):

LB = n(n + 2)[m.summation over (j=1)([[??]sup.2.sub.j]/n x j]) (5)

where n is the sample size. The test statistic is distributed as chi-square with m*k degrees of freedom, where m is the number of autocorrelations and k is the number of estimated parameters in (1). The null hypothesis in this test is that the [[rho].sub.j] autocorrelation coefficients are jointly equal to zero (i.e. the error term is white noise). Rejection of the null implies that the autoregressive process is not white noise.

The DF and ADF test results for LREXP and LRGDP are reported in Table 1. These results imply that the null hypothesis that exports and GDP in log levels are I(1) cannot be rejected. However, the hypothesis that exports and GDP are I(1) in first differences is rejected. Thus, LREXP and LRGDP are non-stationary in levels but stationary in first differences.

To determine if exports and GDP are cointegrated, we use the cointegrating regression with LRGDP as the dependent variable. Thus:

LRGDP = 9.94 + 0.857 LREXP

(0.016) (0.034)

N = 33, [R.sup.2]= .95, D.W. = 1.10, DF = -3.37, SE in parentheses

The null hypothesis is that the error term in the above regression has a unit root (i.e. noncointegration). The critical values for this test at the 5% and 10% level are -3.54 and -3.18. Thus, the null cannot be rejected at the 5% level but is rejected at the 10% level. Based on the above results, we conclude that LRGDP and LREXP are 'weakly' cointegrated.

It is now well-known that cointegration tests have relatively low power of rejecting the null hypothesis of noncointegration. Hakkio and Rush (1991, p.579) point out that "... much of the recent work that has accepted the hypothesis of noncointegration (less formally, rejected cointegration) may be simply the result of very low power. On the other hand, the lack of power suggests that rejecting noncointegration (that is 'accepting cointegration') may be a fairly strong conclusion." Given the small sample size, our results provide some, though not conclusive, evidence of cointegration.

B. Causality Testing and Results

Given that LRGDP and LREXP are 'weakly' cointegrated, we test Granger causality using first differenced variables with and without an error-correction term.

The Granger definition of causality essentially equates causality with predictability. In terms of the export-led growth hypothesis, if GDP growth can be better predicted using past information on both GDP growth and export growth than with just past information on GDP growth alone, then export growth is said to "cause" GDP growth.

An important issue in the empirical implementation of Granger causality is the determination of the optimal lag length of past information. In most of the previous studies on Granger causality, these lags are determined arbitrarily. (3) Akaike's Final Prediction Error (FPE) criterion, however, provides an econometric criterion for determining optimal lag lengths.

In estimating (3) and (4), the lag lengths of p, q, r and s are determined using Akaike's Final Prediction Error (FPE) criterion. The optimal values of p and q in (3) are chosen using a two-stage search procedure. In the first stage, we set q = 0 and search for the optimal value of p ([p.sup.*]) which minimizes:

FPE= n+k/n-k SSR(p)/n

where n is the sample size, SSR(p) is the sum of squared residuals, and k is equal to p + 2 or p + 1 depending upon whether an error-correction term is included or not in (3). In the second stage, we set p = [p.sup.*] and search to find the optimal value of q (q') that minimizes:

FPE([p.sup.*], q) = n + m / n - m SSR([p.sup.*], q) / n

where m =[p.sup.*]+q+2 if an error correction term is included in (3); otherwise, m = [p.sup.*]+ q + 1. (4) Apart from enabling the choice of optimal lag lengths in (3) and (4), the FPE criterion also provides an additional test to determine the direction of causality between exports and GDP growth. Specifically, if FPE([p.sup.*], [q.sup.*]) < FPE([p.sup.*]) then we can infer that x causes y (Giles et al., 1993). Thus, an added advantage of using the FPE method is that it enables us to double-check the Granger causality results.

A second critical issue in testing the ELG hypothesis involves selecting an appropriate regression procedure to estimate equations (3) and (4). Since the focus of this hypothesis is on the simultaneous determination of export growth and economic growth, the issue of a simultaneous equation bias cannot be easily dismissed. When LRGDP and LREXP are I(1) and cointegrated, the OLS estimates of the error-correction model may suffer from a simultaneity bias (Serletis (1992, p. 139)). However, with the exception of Giles et al. (1993), virtually all studies on the export-led growth hypothesis have used Ordinary Least Squares (OLS). One way of overcoming this simultaneity bias is to estimate (3) and (4) simultaneously using the Seemingly Unrelated Regression (SUR) procedure. Table 2 below reports Granger causality test results based on three alternative testing methods: OLS (F statistics), SUR ([chi square] statistics), and Akaike's FPE. The null hypothesis in the F and [chi square] tests is:

a.[d.sub.j] = 0 for j= 1, ... [q.sup.*]

b. [[gamma].sub.j] = 0 for j = 1, ... [s.sup.*]

If both (a) and (b) above are rejected, there is a feedback (y [left and right arrow] x) effect. If (a) is rejected but (b) is not, then x causes y(x [right arrow] y). However, if (a) is not rejected but (b) is rejected, then y causes x(y [right arrow] x). Results for the three methods are reported with and without the inclusion of an error-correction term.

The causality results based on both OLS and SUR estimates indicate that exports ([x.sub.t]) cause economic growth ([y.sub.t]), irrespective of whether we include the error-correction term or not. These results are further reinforced by the fact that FPE([p.sup.*]) > FPE([p.sup.*], [q.sup.*]) and FPE([r.sup.*]) < FPE([r.sup.*], [s.sup.*]). On the other hand, there is little support for the opposite view that economic growth leads to export growth. The invariance of these results across different estimation procedures and across different model specifications suggest that there is strong causality running from exports to economic growth in India.

Conclusion

Using annual data on India's exports and GDP over the 1960-92 pre liberalization period, we analyze the time series properties of these variables in order to determine the appropriate functional form for testing the ELG hypothesis. Since we find that exports and GDP are 'weakly' cointegrated, we test Granger causality using stationary variables with and without an error-correction term. Using three alternative test procedures, we find strong support for uni-directional causality running from exports to economic growth. Furthermore, we find that these results are robust across alternative functional forms (i.e. whether the model includes an error-correction term or not).

Our finding that export performance was an important cause of growth does not by itself explain how exports could have contributed to economic growth in India. There are several possible explanations. Exports may have contributed to economic growth in India directly by relieving severe import constraints, especially in vital capital goods industries. Indirectly, exports may have eased the balance of payments situation and relieved the Indian government of the necessity of pursuing deflationary policies and undertaking difficult structural adjustment programmes such as those undertaken by many developing countries in response to the trade shocks of the seventies and eighties. Another possible explanation involves the existence of strong forward and backward linkages in Indian industries. The dynamic spillover effects from the export sector may have lead to an overall increase in productivity. An interesting avenue for further research is to study the exporteconomic growth relationship at the industry level. An industry level study may provide further insights into the factors that link export expansion to economic growth.

REFERENCES

Ahmad, J. and A.C.C. Kwan (1991), "Causality Between Exports and Economic Growth", Economics Letters, Vol. 37, pp. 243-248.

Anwer, M.S. and R.K. Sampath (2001), "Exports and Economic Growth", Indian Economic Journal, Vol. 47, No. 3, pp. 79-88.

Bhagwati, J. (1978), Foreign Trade Regimes and Economic Development: Anatomy and Consequences of Exchange Control Regime, NBER, New York.

Balassa, B. (1978), "Exports and Economic Growth: Further Evidence", Journal of Development Economics, 5, pp. 181-189.

Chow, P.C.Y. (1987), "Causality Between Export Growth and Industrial Performance: Evidence from the NIC's", Journal of Development Economics, 26, pp. 55-63.

Dhawan, U. and B. Biswal (1999), "Re-Examining Export Led Growth Hypothesis for India: A Multivariate Cointegration Analysis for India", Applied Economics, 31, pp. 525-30.

Engle, R.F. and C.W.J. Granger (1987), "Cointegration and Error Correction: Representation, Estimation and Testing", Econometrica, 55, pp. 251-276.

Engle, R.F. and B.S. Yoo (1987), "Forecasting and Testing in Co-Integrated Systems", Journal of Econometrics, 35, pp. 143-159.

Feder, G. (1982), "On Exports and Economic Growth", Journal of Development Economics, 12, pp. 59-73.

Fung, H.G., B. Sawhney, W.C. Lo and E Xiang (1994), "Exports, Imports and Industrial Production: Evidence from Advanced and Newly Industrializing Countries", International Economic Journal, 8 (4), pp. 87-97.

Giles, D.E.A., J. Giles and E. McCann (1993), "Causality, Unit Roots and Export-led Growth: The New Zealand Experience", Journal of International Trade and Economic Development, pp. 195-218.

Hakkio, C. and M. Rush, M. (1991), "Cointegration: How Short is the Long Run", Journal of International Money and Finance, 10, pp. 571-81.

Hsiao, M.C.W. (1987), "Tests of Causality and Exogeneity between Exports and Economic growth: The Case of the Asian NIC's", Journal of Economic Development, 12, pp. 143-159.

Jung, W.S. and P.J. Marshall (1985), "Exports, Growth and Causality in Developing Countries", Journal of Development Economics, 18, pp. 1-12.

Krueger, A. (1978), Foreign Trade Regimes and Economic Development: Liberalization Attempts and Consequence, NBER, New York.

Kwan, A.C.C. and J. Cotsomitis (1991), "Economic Growth and the Expanding Export Sector: China 1952-1985", International Economic Journal, 5, pp. 105-117.

Little, I.M.D., R. Cooper, W. Corden and S. Rajapatirana (1993), Boom, Crisis, and Adjustment: The Macroeconomic Experience of Developing Countries, Oxford University Press, New York.

Ljung, G.M. and G.P.E. Box (1978), "On a Measure of Lack of Fit in Time Series Models", Biometrika, 66, pp. 66-72.

Mallick, S.K. (1996), "Causality between Exports and Economic Growth in India: Evidence from Cointegration based Error Correction Models", Indian Journal of Economies, 76, (302), pp. 307-20.

Marin, D. (1982), "Is the Export-led Growth Hypothesis Valid for Industrialized Countries", Review of Economies and Statistics, pp. 678-688.

Moosa, I. (1999), "Is the Export Led Growth Hypothesis Valid for Australia", Applied Economics, 31, pp. 903-906.

Nandi, S. and B. Biswas (1991), "Export and Economic Growth in India: Empirical Evidence", Indian Economic Journal, pp. 53-59.

Nidugala, G.K. (2001), "Exports and Economic Growth in India: An Empirical Investigation", Indian Economic Journal, 47(3), pp. 67-78.

Oxley, L. (1993), "Cointegration, Causality and Export-led Growth in Portugal, 1965-1985", Economies Letters, 43, pp. 163-166.

Serletis, A. (1992), "Export Growth and Canadian Economic Development", Journal of Development Economies, 38, pp. 133-145.

Shan, J. and F. Sun (1998), "On the Export Led Growth Hypothesis for the Little Dragons: An Empirical Investigation", Atlantic Economic Journal, 26, pp. 353-71.

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NOTES

(1.) If the error term in noise when (1) is white [[delta].sub.i] = 0, [[for all].sub.i] it is then unnecessary to conduct the ADF test.

(2.) Note that while [z.sub.t-1] is the lagged error term from (2), [z.sub.t-1] is the lagged error term. in the regression [x.sub.t] = [[alpha].sub.0] + [[beta].sub.0] [y.sub.t] [z'.sub.1]

(3.) See, for example, Jung and Marshall (1985), Chow (1987), Hsiao (1987), and Nandi and Biswas (1991).

(4.) The same procedure is used to obtain the optimal lag lengths, [r.sup.*] and [s.sup.*] in (4).

Sudhakar S. Raju, Rockhurst University, Helzberg School of Management, 1100 Rockhurst Road, Kansas City, MO 6411, USA. E-mail: sudhakar.raju@rockhurst.edu

Jacob Kurien, Rockhurst University, Helzberg School of Management, 1100 Rockhurst Road, Kansas City, MO 6411, USA. E-mail: jacob.kurien@rockhurst.edu
Table 1: Stationarity Test Results for LREXP and LRGDP in India,
1960-92

 DF ADF

LREXP -0.0703 0.3562 (1) (a)
LRGDP 0.6849 nn
DLREXP -6.4940 * nn
DLRGDP -8.5301 * nn

(a) The number in parentheses denotes the optimal value of p required
to achieve white noise errors. nn denotes that it was not necessary to
include augmented terms to attain white noise errors.

The asterisk indicates statistical significance at 5% level. The
critical value for n = 50 is -2.93. (Engle and Yoo, 1987).

Table 2: Granger Causality Results: F and [chi square] Statistics

[DELTA] LRGDP = f ([DELTA] LREXP)

 95%
 Critical
 F Value [chi square]

With ECT (a) 5.26 2.74 19.43
Without ECT 5.38 2.87 21.39

[DELTA] LREXP = f ([DELTA] LRGDP)

 95%
 Critical
 F Value [chi square]

With ECT .1839 4.23 0.2125
Without ECT (b) .0004 4.20 0.0021

 95%
 Critical FPE FPE
 Value ([p.sup.*]) ([p.sup.*], [q.sup.*])

With ECT (a) 11.07 0.00128 (1) (b) 0.00093 (1,5)
Without ECT 11.07 0.00128 (1) 0.00096 (1,5)

[DELTA] LREXP = f ([DELTA] LRGDP) s

 95% FPE
 Critical FPE ([r.sup.*], [s.sup.*])
 Value ([r.sup.*])

With ECT 3.84 0.00655 (1) 0.00692 (1,1)
Without ECT (b) 3.84 0.00713 (1) 0.00761 (1,1)

(a) ECT denotes the error-correction term.

(b) The numbers in parentheses are the optimal lag lengths.
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Author:Raju, Sudhakar S.; Kurien, Jacob
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Date:Jun 1, 2005
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