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Trade implications of the Euro in EMU countries: a panel gravity analysis

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Abstract

In this paper, we study the intra-EMU and intra-Eurozone trade effects of the euro adoption on 29 European Economic and Monetary Union countries (including 17 Eurozone economies and Iceland) from the period 1994 through 2011. We employ a generalized gravity model that controls for an extended set of trade theory and policy variables. The gravity model is estimated using the robust panel data techniques that includes times effects, besides country-specific effects. The various econometric specifications of the gravity equation, on the whole dataset of 29 economies, yield positive and significant impact (to be around 14 %) of the euro currency adoption on bilateral trade flows. Next, euro effect on bilateral trade and exports on a smaller dataset is estimated. The estimated results suggest that bilateral trade and exports increase by 20.81 and 18.57 %, respectively, when both the countries belong to the Eurozone. This effect is larger than the one obtained when only one of the two trading partners uses the euro as its currency. In addition, the validity of the assumptions of Heckscher–Ohlin (H–O) theory are checked for the countries under study. The estimated results reject the H–O theory in favor of Modern Trade theories. However, the low value of the coefficient on respective variable suggests that, over the period, the type of trade among these countries has transited from inter-industry trade to horizontal intra-industry trade. This suggests that these developed European economies are on the path of economic convergence via intra-industry trade.

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Notes

  1. For an extensive summary of the various OCA criteria, see Broz (2005).

  2. Although adopted in 1999, the euro was physically introduced in 2002.

  3. By the joining of Latvia to the Euro-zone on January 1, 2014 and Lithuania on January 1, 2015, the number of countries using the euro as its currency has increased to 19.

  4. A one-way FEM permits each cross-sectional unit to have its own constant term while the slope estimates of β are constrained across units, as is the \( \sigma_{\varepsilon }^{2} \). The estimator is termed as least-squares dummy-variable (LSDV) estimator, since it is equivalent to including N − 1 dummy variables in the OLS regression. More specifically, it can be shown to equal the estimator obtained from OLS estimation of \( y_{it} on \, {\mathbf{x}}_{it} \quad \, and \, \quad N \) individual-specific indicator variables \( d_{j,it} , \, \quad j = 1, \ldots ,N \), where \( d_{j,it} , = 1 \) for the ith observation if j = 1, and \( d_{j,it} , = 0 \) otherwise. Then, the fitted model becomes \( y_{it} = \left( {\sum\nolimits_{j = 1}^{N} {\alpha_{i} } d_{j,it} } \right) + {\mathbf{x}}_{it}^{\prime } \beta + \varepsilon_{it} \). However, this equivalence of LSDV and within estimators does not carry over to nonlinear models. Besides, the name LSDV is fraught with problems because it implies an infinite number of parameters in our estimation. A better way to understand the FE estimator is to see that removing panel-level averages from each side of (1) removes the FE from the model, as shown in the methodology part.

  5. Another type of estimator, the between estimator, is less efficient because it discards the over-time information in the data in favor of simple means, as it is the OLS estimator from the regression of \( \bar{y}_{i} \, on \, {\bar{\mathbf{x}}}_{i} \).

  6. In contrast to the FEM (where inference is conditional on the FE in the sample), inference from the REM pertains to the underlying population of individuals because the REM identifies the population parameters that describes the individual-level heterogeneity. Therefore, a REM is more efficient and allows a broader range of statistical inference. However, the key assumption that \( \mu_{i} \) is uncorrelated with the regressors can and should be tested.

  7. As can be seen, RE estimator has pooled OLS (θ = 0) and within estimation (θ = 1) as special cases. The RE estimator approaches the within estimator as T gets large and as \( \sigma_{\mu }^{2} \) gets large relative to \( \sigma_{\varepsilon }^{2} \), because in those cases \( \theta \to 1 \). To the extent that θ differs from 0, pooled OLS will be inefficient, as it will attach too much weight on the between units variation, attributing it all to the variation in \( {\mathbf{x}} \) rather than apportioning some of the variation to the differences in \( \varepsilon_{i} \) across units.

  8. The modern theory of optimum currency areas has shifted its priority from nature and characteristics of an economy to the level of economic development of an economy in judging optimality. In the light of this argument, we preferred per capita GDP to GDP and, hence, retained only per capita GDP variable in our gravity model.

  9. Iceland and Croatia were included being on Exchange Rate Management (ERM II).

  10. Column 4 (two-way FEM) of Table 2 gives the parameter of CU dummy equal to 0.136. Therefore, the increase in bilateral trade induced by the adoption of the euro by euro member countries is [{e 0.136×1 − e 0.136×0} × 100] = 14.57 %.

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Acknowledgments

The authors are very grateful to Ministry of Minority Affairs, Government of India, for funding this research work. The authors are also thankful to Dr. Wasim Ahmad and Ajay Kumar Sahoo for their help from time to time. We also present our special thanks to Prof. Sushant K. Mallick (University of London) and Dr. Ranajoy Bhattacharyya (IIFT, Kolkata Campus) for their views and helpful comments on the study. The earlier versions of this paper were presented at the International Conference on “Global Economic Crisis, Macroeconomic Dynamics, and Development Challenges of Developing Countries” held at Centre for Jawaharlal Nehru Studies, Jamia Millia Islamia University, New Delhi (24–25 Feb. 2014) and at the Two Day National Seminar on “Applications of Panel Data” held, between 25th to 26th of March 2014, in collaboration with The Indian Econometric Society (TIES) at Centre for Economic and Social Studies (CESS), Hyderabad, India.

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Correspondence to Mohd Hussain Kunroo.

Appendix: List of control dummy variables used in the model

Appendix: List of control dummy variables used in the model

All the economic variables that affect trade between the two trading partners are explicitly included in the model. Besides these standard set of gravity variables, there exist a set of control variables that may affect the bilateral trade (such as geographic location, contiguity, landlockedness, historical ties, regional trading agreements and customs union, colonial ties, similarity in cultural, political, and legal institutions, etc.). These variables are classified as economic geography and historical ties variables. Economic geography variables include contiguity and landlocked location. Contiguity may stimulate cross-border trade, while landlocked location may discourage trade between two countries due to lack of sea access. Historical ties variables include common colonial past, common official language, etc. Since our dataset includes only European Union countries, therefore inclusion of variables like colonial ties variable is not required. The included control variables are

  • \( CONTGTY_{ijt} \): dummy variable whose value is equal to 1 if countries i and j share common border in year t and 0 otherwise.

  • \( COMLANGO_{ijt} \): 1 for the common official primary language between country i and country j in year t; 0 otherwise.

  • \( COMLANGE_{ijt} \): 1 if a language is spoken by at least 9 % of the population in both the countries in year t; 0 otherwise.

  • \( LANDLKDI_{it} \): dummy variable whose value is equal to 1 if reporting country i is a landlocked country and partner country j is not in year t and 0 otherwise.

  • \( LANDLKDII_{jt} \): dummy variable whose value is equal to 1 if country i is not a landlocked country but country j is a landlocked country in year t; 0 otherwise.

  • \( LANDLKD_{ijt} \): dummy variable whose value is equal to 1 if both the countries are landlocked in year t and 0 otherwise.

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Kunroo, M.H., Sofi, I.A. & Azad, N.A. Trade implications of the Euro in EMU countries: a panel gravity analysis. Empirica 43, 391–413 (2016). https://doi.org/10.1007/s10663-016-9334-6

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