Abstract
In this paper, we propose a two-market empirical model with heterogeneous agents based on Chiarella et al. (J Econ Behav Organ 83(3):446–460, 2012). Using monthly data of French and US stock markets, the regression shows that individual markets have features of a two-regime switching process. By including inter-market traders whose trading decision is based on fundamental value of foreign market, the two-market model has a better capability in explaining both markets with domestic fundamental traders turning to be significant. The existence of inter-market traders implies that the two markets impact each other through their fundamentals and hence share some common set of factors, which provides foundation of market interactions, such as market co-movement.
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Notes
For simplicity, we remove the superscript for market \(j=\) Fr or US.
References
Boswijk HP, Hommes CH, Manzan S (2007) Behavioral heterogeneity in stock prices. J Econ Dyn Control 31(6):1938–1970
Brock WA, Hommes CH (1998) Heterogeneous beliefs and routes to chaos in a simple asset pricing model. J Econ Dyn Control 22(8–9):1235–1274
Chen Z, Lux T (2017) Estimation of sentiment effects in financial markets: a simulated method of moments approach. Comput Econ. doi:10.1007/s10614-016-9638-4
Chiarella C, Dieci R, He X-Z (2007) Heterogeneous expectations and speculative behavior in a dynamic multi-asset framework. J Econ Behav Organ 62(3):408–427
Chiarella C, Gallegati M, Leombruni R, Palestrini A (2003) Asset price dynamics among heterogeneous interacting agents. Comput Econ 22(2–3):213–223
Chiarella C, He X-Z, Huang W, Zheng H (2012) Estimating behavioural heterogeneity under regime switching. J Econ Behav Organ 83(3):446–460
Day RH, Huang W (1990) Bulls, bears and market sheep. J Econ Behav Organ 14(3):299–329
De Jong E, Verschoor WF, Zwinkels RC (2009) Behavioural heterogeneity and shift-contagion: evidence from the asian crisis. J Econ Dyn Control 33(11):1929–1944
De Jong E, Verschoor WF, Zwinkels RC (2010) Heterogeneity of agents and exchange rate dynamics: evidence from the EMS. J Int Money Finance 29(8):1652–1669
Dieci R, Westerhoff F (2010) Heterogeneous speculators, endogenous fluctuations and interacting markets: a model of stock prices and exchange rates. J Econ Dyn Control 34(4):743–764
Ding Z (2012). An implementation of markov regime switching model with time varying transition probabilities in matlab. Available at SSRN: https://ssrn.com/abstract=2083332 or doi:10.2139/ssrn.2083332
Egert B, Kocenda E (2011) Time-varying synchronization of European stock markets. Empir Econ 40(2):393–407
Fama EF, French KR (2002) The equity premium. J Finance 57(2):637–659
Frijns B, Lehnert T, Zwinkels RC (2010) Behavioral heterogeneity in the option market. J Econ Dyn Control 34(11):2273–2287
Gordon MJ, Shapiro E (1956) Capital equipment analysis: the required rate of profit. Manag Sci 3(1):102–110
Hamilton J (1994) Time series analysis. Princeton University Press, Princeton
He X-Z, Westerhoff FH (2005) Commodity markets, price limiters and speculative price dynamics. J Econ Dyn Control 29(9):1577–1596
Hommes C, Huang H, Wang D (2005) A robust rational route to randomness in a simple asset pricing model. J Econ Dyn Control 29(6):1043–1072
Huang W, Chen Z (2014) Modeling regional linkage of financial markets. J Econ Behav Organ 99:18–31
Huang W, Chen Z (2015) Heterogeneous agents in multi-markets: a coupled map lattices approach. Math Comput Simul 108:3–15
Huang W, Zheng H, Chia W-M (2010) Financial crises and interacting heterogeneous agents. J Econ Dyn Control 34(6):1105–1122
Kenett DY, Raddant M, Zatlavi L, Lux T, Ben-Jacob E (2012) Correlations and dependencies in the global financial village. Int J Mod Phys Conf Ser 16(1):13–28
Kim C-J, Nelson CR (1999) State space models with regime switching: classical and gibbs sampling approaches with applications. The MIT Press
Lux T (1998) The socio-economic dynamics of speculative markets: interacting agents, chaos, and the fat tails of return distributions. J Econ Behav Organ 33(2):143–165
Lux T (2012) Estimation of an agent-based model of investor sentiment formation in financial markets. J Econ Dyn Control 36(8):1284–1302
Manzan S, Westerhoff FH (2007) Heterogeneous expectations, exchange rate dynamics and predictability. J Econ Behav Organ 64(1):111–128
Perez-Quiros G, Timmermann A (2000) Firm size and cyclical variations in stock returns. J Finance 55(3):1229–1262
Perlin M (2012) MS regress—the matlab package for Markov regime switching models. Available at SSRN: http://ssrn.com/abstract=1714016 or doi:10.2139/ssrn.1714016
Preis T, Kenett DY, Stanley HE, Helbing D, Ben-Jacob E (2012) Quantifying the behavior of stock correlations under market stress. Sci Rep. doi:10.1038/srep00752
Schmitt N, Westerhoff F (2014) Speculative behavior and the dynamics of interacting stock markets. J Econ Dyn Control 45:262–288
Westerhoff F, Reitz S (2005) Commodity price dynamics and the nonlinear market impact of technical traders: empirical evidence for the US corn market. Phys A Stat Mech Appl 349:641–648
Westerhoff FH, Dieci R (2006) The effectiveness of Keynes–Tobin transaction taxes when heterogeneous agents can trade in different markets: a behavioral finance approach. J Econ Dyn Control 30(2):293–322
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This project has received funding from the European Union’s Seventh Framework Programme for research, technological development and demonstration under Grant Agreement No. 612955 and the National Natural Science Foundation of China under Grant Agreement No. 71671017. Helpful and stimulating comments by the anonymous reviewer are thankfully acknowledged as well.
Appendix
Appendix
In the main test, the transition probabilities are assumed to be constant. In this section, we evaluate the setting of time varying transition probabilities as a robustness check. Following the method of Perez-Quiros and Timmermann (2000), we assume that the state transition probabilities between periods \(t-1\) and t, \(P_{lk,t}\) for l, \(k=1,2\) are functions of \( y_{t-1}\) which is a vector of state variables:
where \(\varPhi \) is the cumulative density function of a standard normal variable. The use of \(\varPhi \) is to make sure \(0\le P_{lk,t}\le 1\). In our model, the state variable is the relative fundamental price deviation with respect to price for market j, \(x_{t-1}^{j}\):
Depending on the market, the state variable \(y_{t-1}\) can be \(x_{t-1}^{ Fr }\), \(x_{t-1}^{ US }\) or a combination of \(x_{t-1}^{ Fr }\) and \(x_{t-1}^{ US }\) as shown in Table 4 which reports the estimation results using the setting of time varying transition probabilities. The regressions are run using the method of Ding (2012). The regression models are the same as columns 4 and 5 of Table 3. For the French market, the estimation results are qualitatively the same as the ones with the setting of constant transition probabilities, regardless of the choices of state variable \(y_{t-1}\). When \(x_{t-1}^{ Fr }\) acts as the state variable, coefficient of \(x_{t-1}^{ Fr }\) is significant in \(P_{11,t}\). The transition probability of remaining in the low volatility regime for French market increases with the magnitude of the fundamental price deviation of the market itself. The coefficient of \(x_{t-1}^{ Fr }\) is insignificant with a negative value in \(P_{12,t}\), indicating that the transition probability of switching from high to low volatility regimes decreases with \(x_{t-1}^{ Fr }\). The interesting point is that when we utilize \(x_{t-1}^{ US }\) as the state variable for French market, its coefficients have the same sign and significance as \(x_{t-1}^{ Fr }\) in both \(P_{11,t}\) and \(P_{12,t}\). This means the US market has influence on the regime-switching of French market. However, when we include both \(x_{t-1}^{ Fr }\) and \(x_{t-1}^{ US }\) together as components of state variables, their coefficients become highly insignificant in both \(P_{11,t}\) and \(P_{12,t}\). This might be due to the collinearity relationship between \(x_{t-1}^{ Fr }\) and \(x_{t-1}^{ US }\) as the cross-correlation between them is as high as 0.785. For the US market, with \( x_{t-1}^{ US }\) as the state variable, the estimation results are still comparable to those with the setting of constant transition probabilities. However, only a few coefficients are significant. Even for \(P_{11,t}\) and \( P_{12,t}\), the coefficients of \(x_{t-1}^{ US }\) are also insignificant with a positive value in \(P_{11,t}\) and a negative one in \(P_{12,t}\). \(x_{t-1}^{ US }\) plays a role in US similar to \(x_{t-1}^{ Fr }\) in the transition probabilities of French in the way that the transition probability of remaining in the low volatility regime increases with \(x_{t-1}^{ US }\) while the transition probability of switching from high to low volatility regimes decreases with \( x_{t-1}^{ US }\). We further evaluate other choices of state variable by using \( x_{t-1}^{ Fr }\) as well as the joint inclusion of \(x_{t-1}^{ Fr }\) and \( x_{t-1}^{ US }\), the estimations encounter a singular problem with huge error terms and therefore we don’t report these results.
Overall, the estimation results based on the setting of time varying transition probabilities are quite close to the ones based on the constant transition probabilities. The result that \(x_{t-1}^{ US }\) influence the transition probabilities of both US and France indicates that the switching effect might spread from US to France. As \(x_{t-1}^{ Fr }\) is not a state variable to US, we cannot conclude that there is a similar switching effect spreading from France to US.
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Chen, Z., Huang, W. & Zheng, H. Estimating heterogeneous agents behavior in a two-market financial system. J Econ Interact Coord 13, 491–510 (2018). https://doi.org/10.1007/s11403-017-0190-7
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DOI: https://doi.org/10.1007/s11403-017-0190-7