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Measuring Bilateral Market Power in International Markets of Vertically Differentiated Agricultural Commodities

  • Koichi Yamaura EMAIL logo and Tian Xia
Published/Copyright: February 5, 2015

Abstract

Two features of international markets of agricultural commodities are bilateral market power of exporting and importing countries and the coexistence of non-genetically modified (non-GM) and genetically modified (GM) products. The two features were not taken into account in most extant studies on market power in international agricultural commodity markets. This research develops a bilateral oligopoly model with the interaction between non-GM and GM commodity and conducts an empirical estimation for U.S.–Japan soybean trade. The estimation results show that U.S. exporters and Japanese importers are almost equally sharing the dominance of market power. The analysis in this research provides new measures of market power and improves the understanding on world soybean markets.

JEL: Q17; F12; D43

Appendix: Derivation of the degree of dominance (α and 1α) of importers and exporters in terms of market power

The degrees (α and 1α) of dominance of importers and exporters depend on the factors that affect the relative market power of importers and exporters. For importers, the cost shifters for competing soybean importing countries can influence their market power in international markets. The market power of exporters will be affected by the cost shifters for competing soybean exporting countries. In addition, the prices of the vertically differentiated substitute, GM soybeans, will impact the relative market power of importers and exporters. Thus, we specify the degrees (α and 1α) of dominance of importers and exporters as functions of these factors,

α=gWN,RL,PGM,JP,PGM,USand1α=1gWN,RL,PGM,JP,PGM,US

where WN is a vector of the cost shifters for competing soybean exporting countries, RL is a vector of the cost shifters for competing soybean importing countries, PGM,JP and PGM,US are the prices of the vertically differentiated substitute, GM soybeans, in Japan and the United States.

In addition, the functional forms used for α and 1α need to guarantee α0,1 but impose no sign constraints on parameters so that we can allow the flexibility for data to find the sign, magnitude, and significance of the effect of each factor. The functional form, 11+expγX, can keep its value in the range of 0,1 and do not impose sign constraints on the coefficient (γ) of its argument (X), so that we set the degree of dominance as

[6]α=gWN,RL,PGM,JP,PGM,US=11+expΦWN,RL,PGM,JP,PGM,USand
[7]1α=1gWN,RL,PGM,JP,PGM,US=expΦWN,RL,PGM,JP,PGM,US1+expΦWN,RL,PGM,JP,PGM,US.

Then we use a linear functional form for Φ(WN,RL,PGM,JP,PGM,US) in order to avoid too complicated final empirical specification for the econometric model. So we have

[8]ΦWN,RL,PGM,JP,PGM,US=δ1+δ2PGM,JP+δ3PGM,US+ϕWN+τRL,

where δ1, δ2, δ3, ϕ, τ are parameters or vectors of parameters to be estimated. We substitute [8] into [6] and [7] to obtain the specifications for the degrees of dominance of importers and exporters,

[9]α=gWN,RL,PGM,JP,PGM,US=11+expδ1+δ2PGM,JP+δ3PGM,US+ϕWN+τRLand
[10]1α=1gWN,RL,PGM,JP,PGM,US=expδ1+δ2PGM,JP+δ3PGM,US+ϕWN+τRL1+expδ1+δ2PGM,JP+δ3PGM,US+ϕWN+τRL.

The function forms in [9] and [10] can guarantee α0,1 but impose no sign constraints on parameters.

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Published Online: 2015-2-5
Published in Print: 2016-1-1

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