FDI and ECONOMIC GROWTH: Granger Causality Tests in Panel Data Model-Comparative results in the case of European Union countries EU (European Union countries) and ASEAN Association of South East Asian Nations EEFS2008-CONFERENCE June 2009-Warsaw-Poland Argiro Moudatsou 1 Assistant Professor, Technological Educational Institute of Crete Management and Economics School Tourism Department Dimitrios Kyrkilis2 Associate Professor, University of Macedonia, Department of Balkan, Slavic, and Oriental Studies Abstract This study represents an attempt to address the causal-order between inward FDI and economic growth using a panel data set for two different Economic Associations that is EU (European Union) and ASEAN (Association of South Eastern Asian Nations) over the period 1970-2003 The inflows of FDI to developed host countries raise the question of how these inflows affect their economies and what is the interaction between FDI and growth. While there is considerable evidence on the link between FDI and Economic Growth , the causality between them has not been investigated in a reasonable procedure. Three possible cases are investigated in this paper 1) Growth-driven FDI, is the case when the growth of the host country attracts FDI 2) FDI-led growth , is the case when the FDI improves the rate of growth of the host country and 3) the two way causal link between them. Empirical results obtained from heterogeneous panel analysis indicate the following Regarding the EU countries the results support the hypothesis of GDP -FDI causality (growth driven FDI) in the panel Regarding the ASEAN there is evidence that there is a two ways causality between GDP per capita and FDI in the cases of Indonesia and Thailand while in the cases of Singapore and the Philippines FDI is host country GDP growth motivated. JEL Classification, F21, F23,O52 Keywords: Foreign Direct Investment, Economic Growth, Cointegration, Error-correction models and Causality. 1 Postal address: Markou Avgeri 3, 71202 Heraklion Crete- Greece, Tel 30 2810 284682 , e-mail: moudatsou@sdo.teicrete.gr 2 Egnatia 156, P.O. Box 1591, Thessaloniki, Greece 540 06, Tel. +30 2310 891473, e-mail: kyrkilis@uom.gr 1 1. Introduction The relationship between foreign direct investment (FDI) and economic growth is a well-studied subject in the development economics literature, both theoretically and empirically. Recently, renewed interest in growth determinants and the considerable research on externality-led growth, with the advent of endogenous growth theories (Barro, 1991; Barro and Sala-i-Martin, 1995), made it more plausible to include FDI as one of the determinants of long run economic growth. The notion of an investment -development path puts forward the idea that the outward and inward FDI position of a country is systematically related to its economic development relatively to the rest of the world. It suggests that countries tend to go through five different stages of development and that these stages can functionally be classified according to the propensity of outward and/or inward investments (Dunning and Narula 1994, World Investment Report 1995,. pp237, UN). This propensity, in turn, rests on the extent and pattern of the ownership -specific advantages of each country’s indigenous firms, its location advantages and the extent to which indigenous and foreign firms choose to utilise their ownership-specific advantages jointly with the country’s location-bound endowments through an internalization of the crossborder markets for these advantages. Existing empirical evidence, in contrast with more settled theoretical evidence, shows mixed results about the relationship between FDI and economic growth of the host countries. Several reasons may be advanced to explain such disparity of empirical results. To mention a few, first, tests are traditionally conducted using data sets usually belonging to heterogeneous groups of countries while empirical studies use a variety of theoretical models. Second, empirical studies have usually implemented a number of different econometric techniques in testing theoretical models. However, this disparity in results does not preclude the need for further investigation of the subject as long as it is clearly indicated that the analysis and the obtained results are not necessarily generalized to other cases. 2 In this paper the aim is to test for the causal relationship between FDI flows and economic growth for two different groups of countries. The first group is comprised by developing countries, which are members of the Association of South East Asian Nations (ASEAN) and the second group contains a number of fifteen developed countries, which are members of the European Union (EU-15). The idea is to compare the empirically identified relationship between these two different country groups. Inspired by previous results about the impact of FDI on growth the paper seeks to identify systematic patterns in the size of the long run impact of FDI on GDP and/or the opposite, and, in addition to relate the direction of impact on the economic and technological conditions of host countries3 as they differentiate between developed and developing countries. Initially, it is investigated the existence of co integration between GDP growth and FDI flows using the heterogeneous panel co integration test developed by Pedroni (1997, 1999), which allows for cross-sectional interdependency among different individual effects. Next, an Error Correction Model is applied in order to detect the causality between the two variables. 2. Recent literature During the last decade a number of interesting studies of the role of foreign direct investment in stimulating economic growth has appeared. De Mello (1997) lists two main channels through which FDI may be growth enhancing. First, FDI can encourage the adoption of new technologies in the production process through technological spillovers. Second, FDI may stimulate knowledge transfers, both in terms of labour training and skill acquisition and by introducing alternative management practices and better organizational arrangements. A survey by OECD (2002) underpins these observations and documents that 11 out of 14 studies have found FDI to contribute positively to income growth and factor productivity. Both de Mello and OECD stress one key insight from all studies reviewed: the way in which FDI affects growth is likely to depend on the economic and technological conditions in the host country. In particular, it appears that developing countries have to reach a certain level of development, in education and/or infrastructure, before they are able to capture potential benefits associated with FDI. Hence, FDI seems to have more limited growth impact in technologically less advanced countries. 3 See De Mello (1997) 3 Four studies, relying on a variety of cross-country regressions, have looked into the necessary conditions for identifying a positive impact of FDI on economic growth. Interestingly, they stress different, though closely related, aspects of development. First, Blomström et al.(1994) argue that FDI has a positive growth-effect when a country is sufficiently rich in terms of per capita income. Second, Balasubramanyam et al. (1996) emphasize trade openness as being crucial for acquiring the potential growth impact of FDI. Third, Borenztein etal. (1998) find that FDI raises growth, but only in countries where the labour force has achieved a certain level of education. Finally, Alfaro et al. (2004) draw attention to financial markets as they find that FDI promotes economic growth in economies with sufficiently developed financial markets. However, when Carkovic and Levine (2002) estimate the effects of FDI on growth after controlling for the potential biases induced by endogeneity, country-specific effects, and the omission of initial income as a regressor, they find, using this changed specification that the results of these four papers break down. Carkovic and Levine conclude that FDI has no impact on long run growth. Another strand of the literature has focused more directly on the causal relationships between FDI and growth and, at least, six studies have tested for Granger causality between the two series using different samples and estimation techniques. Zhang (2001) looks at 11 countries on a country-by-country basis, dividing the countries according to the time series properties of the data. Tests for long run causality based on an error correction model, indicate a strong Granger-causal relationship between FDI and GDPgrowth. For six counties where there is no co integration relationship between the log of FDI and growth, only one country exhibited Granger causality from FDI to growth. Chowdhury and Mavrotas (2003) take a slightly different route by testing for Granger causality using the Toda and Yamamoto (1995) specification, thereby overcoming possible pre-testing problems in relation to test for co integration between series.2 Using data from 1969 to 2000, they find that FDI does not Granger cause GDP in Chile, whereas there is a bi-directional causality between GDP and FDI in Malaysia and Thailand. De Mello (1999) looks at causation from FDI to growth in 32 countries of which 17 are non-OECD countries. First he focuses on the time series aspects of FDI on growth, finding that the long run effect of FDI on growth is heterogeneous across countries. Second, de Mello complements his time-series analysis by providing evidence from panel data estimations. In the non-OECD sample he finds no causation from FDI to 4 growth based on fixed effects regressions with country specific intercepts, and a negative short run impact of FDI on GDP using the mean group estimator. Nair-Reichert and Weinhold (2001) test causality for cross country panels, using data from 1971 to 1995 for 24 countries. Like de Mello, they emphasize heterogeneity as a serious issue and, therefore, use what they refer to as the mixed fixed and random (MFR) coefficient approach in order to test the impact of FDI on growth. The MFR approach allows for heterogeneity of the long run coefficients, thereby avoiding the biases emerging from imposing homogeneity on coefficients of lagged dependent variables. They find that FDI on average has a significant impact on growth, although the relationship is highly heterogeneous across countries. Choe (2003) uses the traditional panel data causality testing method developed by HoltzEakin et al. (1988) in a data set of 80 countries. His results points towards bi-directional causality between FDI and growth, but he finds the causal impact of FDI on growth to be weak. Basu et al. (2003) addresses the question of the two-way link between growth and FDI. Allowing for country specific co integrating vectors as well as individual country and time fixed effects they find a co integrated relationship between FDI and growth using a panel of 23 countries. Basu et al. emphasise trade openness as a crucial determinant for the impact of FDI on growth, as they find two-way causality between FDI and growth in open economies, both in the short and the long run, whereas the long run causality is unidirectional from growth to FDI in relatively closed economies. Hansen and Rand (2004) using a sample of 31 developing countries and using estimators for heterogeneous panel data, found a bi-directional causality between FDI/GDP and the level of GDP. They interpret this result as evidence in favour of hypothesis that FDI has an impact on GDP via knowledge transfers and adoption of new technology. MAhmoud Al-Iriani and Fatima Al-Shami (2007) testing for the relationship between FDI and growth in the six countries comprising the Gulf Cooperation and using heterogeneous panel analysis methods indicate a bi-directional causality. Their results support the endogenous growth hypothesis for this group of countries. Summing up, the main message to take from this selective survey is that there seems to be a strong relationship between FDI and growth. Although the relationship is 5 highly heterogeneous across countries, the studies generally agree that FDI, on average, has an impact on growth in the Granger causal sense. The main exception from this general conclusion is Carkovic and Levine (2002). 3. Empirical Methodology, Variables, and the Data Set In this paper we estimate the causality between FDI and economic growth in two country groups, namely the EU-15 group, i.e. Austria, Belgium, Cyprus, Denmark, Finland, France, Germany, Greece, Ireland, Italy, Malta, Netherlands, Portugal, Spain, Sweden, and United Kingdom; and the ASEAN group, i.e. Indonesia, Singapore, Philippines, and Thailand. The remaining ASEAN member countries, i.e. Malaysia, Brunei, Lao, Myanmar, Cambodia and Vietnam are not considered because there are numerous missing observations the period under investigation, i.e. 1970 – 2003. The variable economic growth is approximated by the growth of the GDP per capita of country i at a particular time t. The variable FDI is approximated by the ratio of FDI inflows to country I at a time t OVER the Gross Fixed Capital Formation in country i at a time t. The data used are annual and they are sourced in the International Monetary Fund (IMF) and PENNTABLES databases. The estimation is conducted performing the following tests. First, the order of integration of the GDP and FDI time series is tested using the Johansen’s approach. Then, after correcting the time series for stationarity the heterogeneous panel Pedroni (1997, 1999) co integration test is performed for the economic growth and FDI variables. The Pedroni test allows for cross-sectional independency among different individual effects. Second, in order to detect the direction of causality between the two variables the technique of Error Correction Mechanism is applied. 3.1. Heterogeneous Panel Cointegration The concept of co integration was first introduced into the literature by Granger (1980). Co integration implies the existence of a long-run relationship between economic variables. The principle of testing for co integration is to test whether two or more integrated variables deviate significantly from a certain relationship (Abadir and Taylor, 1999). In other words, if the variables are co integrated, they move 6 together over time so that short-term disturbances will be corrected in the long-term. This means that if, in the long-run, two or more series move closely together, the difference between them is constant. Otherwise, if two series are not cointegrated, they may wander arbitrarily far away from each other (Dickey et. al., 1991). Further, Granger (1981) showed that when the series becomes stationary only after being differenced once (integrated of order one), they might have linear combinations that are stationary without differencing. In the literature, such series are called “co integrated”. If integration of order one is implied, the next step is to use co integration analysis in order to establish whether there exists a long-run relationship among the set of the integrated variables in question. Earlier tests of co integration include the simple two-step test by Engle and Granger (EG hereafter) (1987). However, the EG method suffers from a number of problems. Alternatively, Engle and Yoo (1987) (EY, hereafter) 3-step procedure have been widely recognized as dealing with most of these problems. Nevertheless, a problem remains which is that both EG and EY methods cannot deal with the case where more than one co integrating relationship is possible. Hence, Johansen’s Vector Auto Regression (VAR) test of integration (Johansen, 1988) uses a ‘systems’ approach to co integration that allows determination of up to r linearly independent co integrating vectors (r g-1, where g is the number of variables tested for co integration). The Johansen’s procedure is useful in conducting individual co integration tests, but does not deal with co integration test in panel settings. Recognizing the shortcomings of traditional procedures, this study utilized the two types of the heterogeneous panel co integration test developed by Pedroni (1997, 1999) which, in addition to using panel data thereby overcoming the problem of small samples, allows different individual cross-section effects by allowing for heterogeneity in the intercepts and slopes of the co integrating equation. Pedroni’s method includes a number of different statistics for the test of the null of no co integration in heterogeneous panels4. The first group of tests is termed “within dimension”. It includes the panel-v, panel rho(r), which is similar to the Phillips, and Perron (1988) test, panel non-parametric (pp) and panel parametric (adf) statistics. 4 Interested readers may refer to Pedroni (2004) for details and mathematical representations of the tests. 7 The panel non-parametric statistic and the panel parametric statistic are analogous to the single-equation ADF-test. The other group of tests is called “between dimensions”. It is comparable to the group mean panel tests of Im et al. (1997). The “between dimensions” tests include four tests: group-rho, group-pp, and group-adf statistics. The seven of Pedroni’s tests are based on the estimated residuals from the following long run model: m yit i ji x jit it j 1 Where it i i ( t 1) wit are the estimated residuals from the panel regression. The null hypothesis tested is whether i unity is. The seven statistics are normally distributed. The statistics can be compared to appropriate critical values, and if critical values are exceeded then the null hypothesis of no-cointegration is rejected implying that a long run relationship between the variables does exist. 3.2. Causality Tets Pedroni’s heterogeneous panel cointegration method tests only for the existence of long run relationships. The tests indicate the presence or absence of long run links between the variables, but do not indicate the direction of causality when the variables are co integrated. Having detecting the number of co integrated equations (Johansen’s procedure) we used an error correction model (ECM) for a country by country analysis. (Cointegration necessitates that the variables to be integrated are of the same order). If the variables in the model contain unit roots, the Error Correction Model (ECM) is used to examine the long-run or co integrating relationships between the time series as well as the existence and the direction of causality between the variables. The estimated bi-variate ECM for each country takes the following form: ΔGit = α0 + ∑ α1i ΔGit-1 + ∑ α2iΔFDit-1+φECTit-1 +u1it 8 (1) (i=1…n1) (i=1…n2) ΔFDit= b0 + ∑ b1i ΔFDit-1 + ∑ b2iΔGit-1+φECTit-1 +u2it (i=1…n1) (2) (i=1…n2) Where Δ is the difference operator, Gt is the GDP per capita, FDt is the FDI as percentage to gross fixed capital formation, ECTit-1 is the error correction term derived from the long- run co integrating relationship, u1t and u2t are the white noise error terms t denotes the years and n1, n2 are the lag orders of α’s and b’s respectively. The VECM results distinguish between short-run and long-run Granger causality. The coefficients of the lagged error correction term show that there is a long-run causal relationship between economic growth and FDI. It also indicates that FDI and economic growth are adjusting to their long-run equilibrium relationships. The coefficients (and the magnitudes) of the ECM indicate the speed of adjustment to the long-run equilibrium relationship. If φ is statistically significant in the first equation, but not significant in the second then we say that FDI Granger causes GDP, if the opposite happens we say that GDP Ggranger causes FDI. If φ is significant in both equations we say that there is a bidirectional relationship. 4. Results 4.1 Unit-root tests for stationarity The first stage in testing for cointegration between a set of variables is to determine the order of integration of individual time series that is, to determine how many times a variable require inducing stationarity. “If a set of variables are co integrated then there always exists an error correcting formulation of the dynamic model and vice versa (Granger and Engle, 1985). So we run first the ADF tests for stationarity which are performed under three hypotheses: The series are stationary at levels (no unit root), at differencing once (one unit root) at differencing twice (two unit roots). The series of economic growth and FDI for almost all countries in both samples have one unit root so we take the first differences and then run cointegration tests. 9 In the case of the EU-group and in particular for the cases of Austria, Cyprus, Denmark, Finland, France, Germany, Italy, Netherlands, Portugal, Spain, Sweden, United Kingdom. There were found two co integrated equations while in the cases of Greece, Ireland, and Malta it was found on co integrated equation, and none co integrated equation for Belgium, and Spain. In the case of the ASEAN group two co integrated equation were found for all countries of the group. 4.2 Panel cointegration tests (PEDRONI) We take the first difference of the series in both samples and then we run the Pedroni’s test for the panel cointegration. Table 1. Pedroni’s Heterogeneous Panel Cointegration Test Results ASEAN-group Test Statistics Value panel v-stat 0.19778 panel rho-stat -7.77843 panel pp-stat -11.80177 panel adf-stat -9.37884 group rho-stat -5.27172 group pp-stat -11.31416 group adf-stat -9.50582 All except the first one sre significant at 5% level Nsecs = 4, TPeriods = (unbalanced), no. regressors = 1 All reported values are distributed N (0, 1) under null of unit root or no cointegration. Panel stats are weighted by long run variances 10 Table 2. Pedroni’s Heterogeneous Panel Co integration Test Results EU group Test Statistics Value panel v-stat -0.08211 -14.49312 panel rho-stat panel pp-stat -26.13542 panel adf-stat -16.91834 group rho-stat -11.22026 group pp-stat -28.26462 group adf-stat -17.96417 All except the first one ore significant at 5% level Nsecs = 13, TPeriods = (unbalanced), no. regressors = 1 All reported values are distributed N (0, 1) under null of unit root or no cointegration. Panel stats are weighted by long run variances The Pedroni’s tests indicate that there is a long-run relationship between FDI and GDP for both Associations. We proceed to test for causality direction using Error Correction model for each country (see the equations 1,2 in section 5 of this paper) 4.3 Causality through ECM models The results from the error correction equations are reported below in Table 3: 11 Table 3. ECM Estimates of Causality between FDI and GDP EU group AIRTSUA SUFSIR DRAMASD PUALAAD PSAASR IRSMAAU ISRRSR USRLAAD UTALU MALTA ARTARSLAADR FASTIIAL RERDRA IDF sescac PDU sescac PDU IDF IDF sescac PDU PDU sescac IDF PDU sescac IDF IDF sescac PDU IDF sescac PDU IDF sescac PDU IDF sescac PDU IDF sescac PDU yaseaetuen IDF sescac PDU DF sescac PDUI UADAARRUA TAAULAAD RUAIAFASR FAULUFUARR Sescetuen uy ouen uaaseuuyc Sescetuen uy ouen uaaseuuyc IDF sescac PDU IDF sescac PDU ASEAN group 5. Conclusions The findings confirm the strong and positive relationship between economic growth of the host country and FDI inflows in both developed and developing countries. However, this relationship runs from economic growth to FDI in the case of the developed countries while the picture is mixed in the case of the developing countries. In the ASEAN group both directions causality is detected in the cases of Indonesia and Thailand compared with a conventional economic growth induced FDI inflow in the cases of Singapore and the Phillipines. Economic growth is rather promoted by technological spillovers and diffusion than any other mechanism advancing GDP. In the case of developed economies host countries are already technologically advanced and there is little scope for any impact of technologies transferred from the investing foreign companies. On the contrary, in the case of developing nations there is a 12 technology gap between them and the FDI source countries, which are rather developed ones, and there is scope for technology diffusion subject to the ability of the host country to absorb and utilize the transferred technologies. This ability depends on the institutions, human capital, and other infrastructure available in the country. 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