Abstract
Using an econometric shift-share decomposition, we explain the redistribution of world market shares at the level of the product variety and by technological content. We decompose changes in market shares into structural effects (geographical and sectoral) and a pure performance effect. We regard the EU-27 as an integrated economy, excluding intra-EU trade. Revisiting the competitiveness issue in such a perspective sheds new light on the impact of emerging countries on the reshaping of world trade. Since 1995 the EU-27 withstood the competition from emerging countries better than the United States and Japan. The EU market shares for high-technology products, as well as in the upper price range of the market, proved comparatively resilient, though less so since the crisis.
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Notes
67 % of EU-27 exports are within the Single European Market, where most European countries record larger market shares thanks to better market access.
The extensive margin of exports so defined should not be confused with the heterogeneous firms settings where trade introduces a selection between firms, as well as, in case of multi-product firms, a selection within the portfolio of products of each exporter.
Hummels and Klenow (2005) draw on HS6 data on exports in 1995 by 110 countries to 59 importers. Alternatively, they use United States imports from 119 countries in over 13,000 10-digit United States tariff lines for the same year. Our approach also differs from Besedes and Prusa (2011) who integrate the time dimension into the analysis of export growth and breakdown the intensive margin into a survival and a deepening component.
Zipped file at the working paper version webpage of this work.
Wang and Wei (2010) use export at product level for different Chinese cities and point to the role of human capital and government intervention in shaping a specialization that increasingly overlaps with that in high-income countries.
The term g t S t−1 i vanishes because g t = 0.
\(SECT_i = \prod\limits_t {\left[1 + \sum\nolimits_k {\left( {g_k}^t \right)\left({S_{ik}^{t-1}}/{S_{i}^{t-1}}\right)} \right]}, \; \; GEO_i = \prod\nolimits_t {\left[1 + \sum\nolimits_{jk} {\left( {g_{jk}^t - g_k^t }\right)\left({S_{ijk}^{t-1}}/{S_{i}^{t-1}}\right) } \right]}, PERF_i = \prod\nolimits_t {\left[1 + \sum\nolimits_{jk} {\left({\left({S_{ijk}^t}/{S_{i}^{t-1}}\right) - \left({S_{ijk}^{t-1}}/{S_{i}^{t-1}}\right)(1+g_{jk}^t )} \right)} \right]} + e_i - 1\).
See footnote 9.
\({PERF_i^\star} = \prod\nolimits_t {\left[1 + \sum\nolimits_{jk} {\left({\left({S_{ijk}^t}/{S_{i}^{t-1}}\right) - \left({S_{ijk}^{t-1}}/{S_{i}^{t-1}}\right)(1+g_{jk}^t )} \right)} \right]} * v_i\).
The traditional shift-share analysis is actually a constrained and imperfect version of regression and variance analysis techniques.
The Törnqvist index is the weighted geometric average of the relative change between the current and base period where weights are the arithmetic average of the market shares in the two periods.
Although at the exporter/importer/product level the difference between growth rates computed according to the two sides of the above equation may vary significantly, the weighted averages at the level of each exporter are very similar. For example for France the difference between the two weighted means represents at most 6 % of the largest of the two values. For Germany the difference is even smaller.
The last constraint is implicitly imposed when estimating (7) with weighted OLS.
Dropping the constant permits to keep all exporter fixed-effects.
Accordingly, we have \(\; d\ln X^{95-10} \equiv \sum\nolimits_t \left(d\ln X^t \right) = \sum\nolimits_t \left( \sum\nolimits_{i} w_i^t \; d\ln{X_i^t}\right)\).
\({d}\ln X_i^{95-10} \approx \ln \left( X_i^{2010}/X_i^{1995}\right) \;\) and \(\; {d}\ln X^{95-10} \approx \ln \left(X^{2010}/X^{1995}\right)\).
Actual (true) market share growth rates are obtained as \(\; \left(\frac{X_i^{2010}}{X^{2010}} - \frac{X_i^{1995}}{X^{1995}} \right)/\left(\frac{X_i^{1995}}{X^{1995}}\right)\).
As mentioned above and in the data "Appendix", we eliminate from our sample the noise associated with very small values (below USD 10,000), non-independent territories and micro-states, and drop HS sections 25, 26, 27, 97, 98, 99 (mineral, specific and non-classified products).
\(\bar{X}_{i}^{2010}=\bar{X}_{i}^{1995}+\sum\nolimits_{t=1995}^{2010} \sum\nolimits_{jk}{\left({X}_{ijk}^{t+1}-{X}_{ijk}^{t}\right)*\hbox{I}\left[X_{ijk}^t\neq 0\cap X_{ijk}^{t+1}\neq 0\right]}\).
\(\bar{X}^{t}=\sum\nolimits_{i}\bar{X}_{i}^{t}\).
China’s 1995–2010 intensive margin accounted for 11.35 p.p. of the overall global market (including both flows that survive and vanish from year to year), and for 12.14 p.p. of the global market computed on the intensive margin (as the sum of flows that exist as well in the previous and/or following year). These changes represent, respectively, 180.0 and 188.5 % of the corresponding global markets. When export growth rates are computed with the Törnqvist approximation, the 188.5 % Chinese market share growth becomes 192.3 %.
As confirmed by Beltramello et al. (2012) using our methodology and data, the sectoral effect is negative for most emerging exporters, reflecting their specialization toward more traditional, lower technology industries. The CMS analysis from Crespo and Fontoura (2010), which uses a panel similar to ours, also provides evidence of the growth of market share of many emerging countries in Asia and Central and Eastern Europe, despite their negative sector and /or geographical structure effects.
Detailed results by individual EU-27 countries are available in the online Appendix.
Non-shifters (e.g. top-range in t 0 and t 1) are indeed kept in their initial range.
Different versions of BACI data are updated and available at the CEPII webpage to COMTRADE users.
More precisely, we exclude the six following chapters of the Harmonized System: the mineral products (chapters 25, 26 and 27), the works of art, collectors’ pieces and antiques (chapter 97) and the two last chapters, 98 and 99, devoted to special classifications or transactions.
Zipped file at the working paper version webpage of this work and authors’ personal webpages.
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Acknowledgments
We are indebted to an anonymous referee for helpful remarks and suggestions on a previous version. We would also like to thank the participants in the Banque de France Seminar, the PSE-GmonD Conference on Quality and Trade, and the XII Conference on International Economics (Castellón), as well as Charlotte Emlinger, Guillaume Gaulier, Luciana Juvenal and Julia Wörz for their comments. The views are those of the authors. The usual disclaimer applies.
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Appendix
Appendix
1.1 Data description
The trade data used in this paper are from the BACI database, a database for the analysis of international trade at the product-level developed by Gaulier and Zignago (2010). BACI draws on the UN COMTRADE information, in which imports are reported CIF (cost, insurance and freight) and the exports FOB (free on board). BACI provides reconciled FOB data on trade flows: for a given product k and a given year t, exports from country i to importer j are equal to j imports from i. This reconciliation of mirror flows is performed for both values and quantities, and relies on estimated indicators of the reliability of import and export country reports. The quantity units are converted into tons, making possible the computation of homogeneous unit values. Footnote 28
BACI covers trade between more than 200 countries, in the roughly 5,000 products of the 6-digit Harmonised System (HS6) classification. However, this study excludes intra-EU-27 trade flows. This choice must be borne in mind when it comes to market shares and changes therein. We also exclude mineral, specific and non-classified products.Footnote 29 Trade flows below USD 10,000 and involving non-independent territories and micro-states are also excluded in Sect. 2.1 and in Sect. 3 For the shift-share analysis in Sect. 3 we employ HS2 data obtained by aggregation of HS6 data. The motivation behind is to keep a larger share of trade flows in the intensive margin, the only component of the export growth discussed in that section.
Concerning the high-tech products, we use the classification in broad sectors proposed by Lall (2000), detailed in Table 9.
The availability of traded unit values at a very disaggregated level (country-partner-product-year) in the BACI database makes it possible to compute international trade price indices. Similar to Gaulier et al. (2008), we compute price indices as chained Törnqvist indices of unit values, but unlike them we compute an index for each pair of trading countries (exporter-importer) and HS2 heading. Data in 2,000 is taken as reference. We use these indices to deflate trade values (expressed in current USD in BACI) to obtain trade volumes expressed in terms of 2,000 prices. Since this exercise allows us to disentangle price effects, we refer to obtained data as volumes.
The world distribution of unit values for each HS6 heading allows us to classify each product-bilateral flow into three price segments, and to examine competition among the main world exporters within each of these segments. Trade flows are ordered according their unit values and classified as follows: flows with the lowest unit value form the bottom-range, the ones with intermediate unit values—the mid-market, and the ones with the highest unit value—the mid-range. We employ the technique developed by Fontagné et al. (2008) to construct the three market segments. There is also a small “non-classified” range of trade flows for which data on trade quantities is not available and unit values cannot be computed, but they represent <10 % of world trade.
Tables of this paper display results for countries accounting for more than 1 % of world exports from 1995 to 2010. Results for countries accounting for <1 % of world exports from 1995 to 2010 are aggregated within three groups: the Middle East and North Africa (MENA), Sub-Saharan Africa (SSA), and Rest of the World (RoW). Results for all other countries in the world are available in our online appendix. Footnote 30
1.2 Additional results
See Tables 10, 11 and Figs. 4, 5.
1.3 Computation of standard errors
One of the advantages of the econometric shift-share approach, with respect to the traditional approach, is the estimation of standard errors for each effect. Effects Perf i , Geo i , and Sect i of the decomposition of market share growths, given by Eq. (13), are computed from exporter, importer and sector fixed effects α t i , β t j , γ t k estimated with Eq. (7). Summarizing the computations in Sect. 3.2, we have:
One can use the standard errors of these effects to predict the statistical significance of country-level export performance and structural effects. We compute standard deviations for terms Perf i , Geo i , and Sect i using the so-called Delta method, as the diagonal of square matrices \(S = \left( A \Upomega A^T \right)^{1/2}\), where A is the matrix of partial derivatives of effects Perf i , Geo i , or Sect i with respect to the vector of all estimated effects \({\bf v} = (\alpha_i^{t} \; \beta_j^{t} \; \gamma_k^{t})\), and \(\Upomega\) is the variance-covariance matrix of effects α t i , β t j , γ t k estimated with Eq. (7). Note that the covariance of different type of effects is equal to zero: \(\Upomega = \left(\begin{array}{ccc} \sigma(\alpha_i^t)^2 & 0 & 0 \\ 0 & \sigma(\beta_j^t)^2 & 0 \\ 0 & 0 & \sigma(\gamma_k^t)^2 \\ \end{array}\right)\).
Using the definition of Perf i , Geo i , or Sect i (see above), we have:
where \(i,l=\overline{1,I}, \; j,d=\overline{1,J}, \; k,m=\overline{1,K}, \;\) and \(\; t=\overline{1,T}\).
The standard errors of shift-share decomposition effects are obtained as follows:
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Cheptea, A., Fontagné, L. & Zignago, S. European export performance. Rev World Econ 150, 25–58 (2014). https://doi.org/10.1007/s10290-013-0176-z
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DOI: https://doi.org/10.1007/s10290-013-0176-z