Abstract
This article critically investigates the possibility that private information offering systematic profit opportunities exists in the spot foreign exchange market. Using a unique dataset with trader-specific limit and market order histories for more than 10,000 traders, we detect transaction behavior consistent with the informed trading hypothesis, where traders consistently make money. We then work within the theoretical framework of a high-frequency version of a structural microstructure trade model, which directly measures the market maker’s beliefs. Both the estimates of the trade model parameters and our model-free analysis of the data suggest that the time-varying pattern of the probability of informed trading is rooted in the strategic arrival of informed traders on a particular day-of-week, hour-of-day, or geographic location (market).
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Notes
As in Dacorogna et al. (2001) and, recently, Kaul and Sapp (2009), we use the following geographic regions to cover the 24-h trading day: 03:00–07:00 EST (Europe only), 07:00–11:00 EST (both Europe and North America), 11:00–15:00 EST (North America only), 15:00–19:00 EST (post-North America), and 19:00–03:00 EST (Asia).
For example, in the framework by Lyons (2001), customers are the primary source of private information, but the implications of their strategic behavior are not considered.
This line of reasoning has also been documented for equity markets. For example, Foster and Viswanathan (1994) find that the optimal strategy of better informed traders is to delay trading on his or her private information in the early rounds of trading, while trading very intensely on the common information.
See Triennial Central Bank Survey of Foreign Exchange and Derivatives Market Activity in April 2010: http://www.bis.org/publ/rpfxf10t.
We are grateful for this and other useful comments from an anonymous referee.
One basis point is defined as 1/100th of a percentage point.
In 2003/2004, the platform of OANDA did not have many decision support tools, so the traders were not well connected to the professional trading community. If traders can generate profits in a highly liquid and efficient market, such as the FX market, without access to “inside” information, then this raises interesting questions of why and how this can be feasible.
By “active,” we refer to traders that did not simply receive interest on their positions, but placed orders during this period. The market share of these traders is approximately 86.4 %.
The next most active currency pairs are USD-CHF (7.88 % share), GBP-USD (7.81 % share), USD-JPY (6.42 % share), and AUD-USD (5.98 % share).
Of the 10,000 registered traders, about 5,000 were active in the EUR–USD trading over the sample period.
Trader ID is withheld to preserve data confidentiality.
We also plot the hour-of-day indices for the raw data that use unadjusted \(B_t\) and \(S_t\) (dashed line). Similar arrival patterns are observed for the two types of traders. Thus, “hidden” hour-of-day patterns are present even after \(B_t\) and \(S_t\) are de-seasonalized. Since these effects are strong enough to persist even after adjusting for intraday time dependency, we will concentrate on the de-seasonalized data for the remainder of the paper.
The day-of-week indices, denoted by \(SI_i\) (\(i\in \{\alpha , \delta , \varepsilon , \mu , \mathrm{PIN}\}\)), are found using the ratio-to-moving average method.
The estimates over 145 days are stable with regard to the reasonable choice of their starting values. The only case in which the estimates begin to substantially change is when \(\mu _0>200\) and \(\varepsilon _0>200\).
Easley et al. (1997b) test for the independence assumption and find that information events in their dataset are independent.
Under the null hypothesis of the randomness of information events across hours, the total number of runs \(r\) (sequences of ones or zeros) is normally distributed with \(\bar{r}=\frac{2e_i n_i}{e_i+n_i} +1\) and \(\sigma _r^2=\frac{(\bar{r} -1)(\bar{r}-2)}{(e_i+n_i)-1}\).
For the null hypothesis of independence (or randomness) of information events over \(I\)=24 h, this test is based on the following statistic: \(Q_L=I(I+2)\sum _{\tau =1}^{L}\frac{\hat{\rho }^2_\tau }{I-\tau }\), where \(L\) is typically chosen to be substantially smaller than \(I\) and \(\hat{\rho }^2_\tau \) is the sample autocorrelation coefficient at lag \(\tau \).
One may expect the arrival of informed traders to be related only to the information flow. However, in this setting, they appear to use their private information strategically. Another possibility is that informed traders enter the market not only to establish speculative positions (information effects), but also to adjust their currency inventory (inventory effects), as previously mentioned.
Cubic spline is an interpolation method that fits a curve by constructing piecewise third-order polynomials that pass through original data points (Burden and Faires 2004).
The Granger causality tests for the hourly arrivals yield findings similar to those for the daily arrival rates: \(TT_t - |K_t|\) Granger-causes \(|K_t|\), but not vice-versa.
This assumption may seem inappropriate, given that it rules out any strategic behavior. As shown in Sect. 2.3, informed traders have some tendency to trade strategically. Therefore, we concur that the assumption of risk neutrality needs defending, but we retain it for the sake of the model applicability.
To derive Eq. (11), the term \(\ln [x^{M_i}(\mu +\varepsilon )^{B_i+S_i}]\) is simultaneously added to the first sum and subtracted from the second sum in Eq. (10). This is done to increase computational efficiency and to ensure convergence in the presence of a large numbers of buys and sells, as is the case in our dataset.
References
Albuquerque R, De Francisco E, Marques L (2008) Marketwide private information in stocks: forecasting currency returns. J Finance 63(5):2297–2343
Bjønnes G, Rime D (2005) Dealer behavior and trading systems in foreign exchange markets. J Finan Econ 75(3):571–605
Bjønnes G, Osler C, Rime D (2008) Asymmetric information in the interbank foreign exchange market, norges Bank Working Paper
Boehmer E, Grammig J, Theissen E (2007) Estimating the probability of informed trading—does trade misclassification matter? J Finan Mark 10(1):26–47
Breedon F, Ranaldo A (2013) Intraday patterns in FX returns and order flow. J Money Credit Bank 45(5):953–965
Burden R, Faires JD (2004) Numerical Analysis. Brooks Cole, Florence
Covrig V, Melvin M (2002) Asymmetric information and price discovery in the FX market: does Tokyo know more about the yen? J Empir Finance 9:271–285
Dacorogna M, Gençay R, Muller U, Olsen R, Pictet O (2001) An introduction to high-frequency finance. Academic Press, San Diego
D’Souza C (2008) Price discovery across geographic locations in the foreign exchange market. Bank of Canada Review pp 17–25
Easley D, O’Hara M (1992) Time and the process of security prices adjustment. J Finance 47:577–605
Easley D, Kiefer N, O’Hara M (1996a) Cream-skimming or profit-sharing? The curious role of purchased order flow. J Finance 51:811–833
Easley D, Kiefer N, O’Hara M, Paperman J (1996b) Liquidity, information and infrequently traded stocks. J Finance 51:1405–1436
Easley D, Kiefer N, O’Hara M (1997a) The information content of the trading process. J Empir Finance 4:159–185
Easley D, Kiefer N, O’Hara M (1997b) One day in the life of a very common stock. Rev Finan Stud 10:805–835
Easley D, Engle R, O’Hara M, Wu L (2008) Time-varying arrival rates of informed and uninformed trades. J Finan Econ 6(2):171–207
Evans M, Lyons R (2002) Order flow and exchange rate dynamics. J Political Econ 110:170–180
Evans M, Lyons R (2005) Meese-rogoff redux: micro-based exchange rate forecasting. Am Econ Rev 95(2):405–414
Evans M, Lyons R (2012) Exchange rate fundamentals and order flow. Q J Finance 2(4):1250,018
Foster F, Viswanathan S (1994) Strategic trading with asymmetrically informed traders and long-lived information. J Finan Quant Anal 29(4):499–518
Gallant A, Rossi P, Tauchen G (1992) Stock prices and volume. Rev Finan Stud 5(2):199–242
Gençay R, Gradojevic N (2013) Private information and its origins in an electronic foreign exchange market. Econ Model 33:86–93
Goldstein M, Van Ness BF, Van Ness RA (2006) The intraday probability of informed trading on the NYSE. Adv Quant Anal Financ Acc 3:139–158
Gradojevic N (2007) The microstructure of the Canada/U.S. dollar exchange rate: a robustness test. Econ Lett 94(3):426–432
Hau H (2001) Location matters: an examination of trading profits. J Finance 56(5):1959–1983
Heimer R, Simon D (2012) Facebook finance: how social interaction propagates active investing, brandeis University Working Paper
Kaul A, Sapp S (2009) Trading activity, dealer concentration and foreign exchange market quality. J Bank Finance 33(11):2122–2131
King M, Rime D (2010) The \({\$}4\) trillion question: What explains FX growth since the 2007 survey? BIS Quarterly Review pp 27–42
Lee C, Ready M (1991) Inferring trade direction from intraday data. J Finance 46:733–746
Lei Q, Wu G (2005) Time-varying informed and uninformed trading activities. J Finan Mark 8(2):153–181
Ljung G, Box G (1978) On a measure of lack of fit in time series models. Biometrika 65:297–303
Lyons R (1995) Test of microstructural hypotheses in the foreign exchange market. J Finan Econ 39:321–351
Lyons R (2001) The microstructure approach to exchange rates. The MIT Press, Cambridge
Madhavan A, Smidt S (1993) An analysis of changes in specialist inventories and quotations. J Finance 48:1595–1628
Marsh IW, O’Rourke C (2005) Customer order flow and exchange rate movements: Is there really information content?, working Paper
Menkhoff L, Schmeling M (2008) Local information in foreign exchange markets. J Int Money Finance 27(8):1383–1406
Menkhoff L, Schmeling M (2010) Whose trades convey information? Evidence from a cross-section of traders. J Finan Mark 13(1):101–128
Moore M, Payne R (2011) On the sources of private information in FX markets. J Bank Finance 35(5):1250–1262
Nolte I, Nolte S (2012) How do individual investors trade? Eur J Finance 18(10):921–947
Odders-White ER, Ready MJ (2008) The probability and magnitude of information events. J Finan Econ 87(1):227–248
Osler C, Vandrovych V (2009) Hedge funds and the origins of private information in currency markets, working Paper No. 1484711
Payne R (2003) Informed trade in spot foreign exchange markets: an empirical investigation. J Int Econ 61:307–329
Peiers B (1997) Informed traders, intervention, and price leadership: a deeper view of the microstructure of the foreign exchange market. J Finance 52(4):1589–1614
Ranaldo A (2009) Segmentation and time-of-day patterns in foreign exchange markets. J Bank Finance 33(12):2199–2206
Shapiro S, Wilk M (1965) An analysis of variance test for normality (complete samples). Biometrika 52(3–4):591–611
Venter J, De Jongh D (2004) Extending the ekop model to estimate the probability of informed trading, working Paper
Vitale P (2012) Optimal informed trading in the foreign exchange market. Eur J Finance 18(10):989–1013
Wuensche O (2007) Using mixed Poisson distributions in sequential trade models, working Paper
Yao J (1998) Market making in the interbank foreign exchange market, working Paper No. S-98-3
Acknowledgments
We are grateful to Olsen Ltd. (www.olsen.ch), Switzerland for providing the data.
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Ramazan Gençay and Nikola Gradojevic gratefully acknowledge financial support from the Natural Sciences and Engineering Research Council of Canada and the Social Sciences and Humanities Research Council of Canada.
Faruk Selçuk passed away during this research.
Appendices
Appendix 1: independent arrival model (Easley et al. 1996b)
The model consists of informed and uninformed traders and a risk-neutral competitive market maker. The traded asset is a foreign currency for the domestic currency. Similar to the portfolio shifts model (Evans and Lyons 2002), the trades and the governing price process are generated by the quotes of the market maker over a 24-h trading day. Within any trading hour, the market maker is expected to buy and sell currencies from his posted bid and ask prices. The price process is the expected value of the currency based on the market maker’s information set at the time of the trade.
The hourly arrival of news occurs with the probability \(\alpha \). This represents bad news with probability \(\delta \) and good news with \(1-\delta \) probability. Let \(\{p_{i}\}\) be the hourly price process over \(i=1,2,\ldots ,24\) h. \(p_{i}\) is assumed to be correlated across hours and will reveal the intraday time dependence and intraday persistence of the price behavior across these two classes of traders. The lower and upper bounds for the price process should satisfy \(p_{i}^{b} < p_{i}^{n} < {p_{i}^{g}}\) where \(p_{i}^{b}\), \(p_{i}^{n}\), and \(p_{i}^{g}\) are the prices conditional on bad, no news, and good news, respectively. Within each hour, time is continuous and indexed by \(t \in [0,T]\).
In any trading hour, the arrivals of informed and uninformed traders are determined by independent Poisson processes. At each instant within an hour, uninformed buyers and sellers each arrive at a rate of \(\varepsilon \). Informed traders only trade when there is news, and arrive at a rate of \(\mu \). All informed traders are assumed to be risk neutral and competitive and are therefore expected to maximize profits by buying when there is good news and selling otherwise.Footnote 25 For good news hours, the arrival rates are \(\varepsilon + \mu \) for buy orders and \(\varepsilon \) for sell orders. For bad news hours, the arrival rates are \(\varepsilon \) for buy orders and \(\varepsilon + \mu \) for sell orders. When no news exists, the buy and sell orders arrive at a rate of \(\varepsilon \) per hour.
The market maker is assumed to be a Bayesian who uses the arrival of trades and their intensity to determine whether a particular trading hour belongs to a no news, good news, or bad news category. Since the arrival of hourly news is assumed to be independent, the market maker’s hourly decisions are analyzed independently from 1 h to the next. Let \(P(t) = (P_n(t), P_b(t), P_g(t))\) be the market maker’s prior beliefs with no news, bad news, and good news at time \(t\). Accordingly, his or her prior beliefs before trading starts each day are \(P(0) = (1-\alpha , \alpha \delta , \alpha (1-\delta ))\).
Let \(S_t\) and \(B_t\) denote sell and buy orders at time \(t\). The market maker updates the prior conditional on the arrival of an order of the relevant type. Let \(P(t|S_{t})\) be the market maker’s updated belief conditional on a sell order arriving at \(t\). \(P_n(t|S_{t})\) is the market maker’s belief about no news conditional on a sell order arriving at \(t\). Similarly, \(P_{b}(t|S_{t}) \) is the market maker’s belief about the occurrence of bad news events conditional on a sell order arriving at \(t\), and \(P_{g}(t|S_{t})\) is the market maker’s belief about the occurrence of good news conditional on a sell order arriving at \(t\).
The probability that any trade occurring at time \(t\) is information based is (please see Appendix 2)
Since each buy and sell order follows a Poisson Process at each trading hour and orders are independent, the likelihood of observing a sequence of orders containing \(B\) buys and \(S\) sells in a bad news hour of total time \(T\) is given by
where \(\theta =( \alpha ,\delta ,\varepsilon ,\mu ) \).
Similarly, in a no-event hour, the likelihood of observing any sequence of orders that contains B buys and S sells is
In a good-event hour, this likelihood is
The likelihood of observing \(B\) buys and \(S\) sells in an hour of unknown type is the weighted average of Eqs. (2), (3), and (4) using the probabilities of each type of hour occurring.
Because hours are independent, the likelihood of observing the data \(M=( B_{i},S_{i}) _{i=1}^{I}\) over 24 h \((I=24)\) is the product of the hourly likelihoods,
The log likelihood function is
As in Easley et al. (2008), the log likelihood function, after dropping the constant and rearranging,Footnote 26 is given by
where \(M_i\equiv \min (B_i,S_i) + \max (B_i,S_i)/2\), and \(x =\frac{\varepsilon }{\varepsilon +\mu } \in [0,1]\).
Appendix 2: derivation of the PIN
By Bayes’ rule, the market maker’s posterior probability with no news at time \(t \), if an order to sell arrives at \(t\), is
where \(P_{n}( S_{t}|t ) \) is the probability of the arrival of a sell order conditional on no news at time \(t\), \(P_{g}( S_{t}|t ) \) is the probability of the arrival of a sell order conditional on good news at time \(t\), and \(P_{b}(S_{t}|t ) \) is the probability of the arrival of a sell order conditional on bad news at time \(t\).
Similarly, the posterior probability on bad news is
and the posterior probability on good news is
The bid price, \(b(t)\), conditional on \(S_{t}\) at time \(t\) at hour \(i\) is
Similarly, the ask price \(a(t) \) is the market maker’s expected value of the asset conditional on the history prior to \(t\) and on \(B_{t}\).
Thus, the ask at time \(t\) at hour \(i\) is
The expected price conditional on \(t\) is
where \(P_{n}( t) \), \(P_{b}( t) \) and \(P_{g}( t) \) are the prior beliefs of the market maker for no news, bad news, and good news at time \(t\).
Substituting the expected price equation into the equations for bid and ask prices yields
and
Let \(d(t) =a(t)-b(t) \) be the spread at time \(t\).
The spread for the opening quotes is
If good and bad events are equally likely, that is, if \(\delta =1-\delta \) , \(\delta =0.5\). Thus
The probability that any trade occurring at time \(t\) is information based is
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Gençay, R., Gradojevic, N., Olsen, R. et al. Informed traders’ arrival in foreign exchange markets: Does geography matter?. Empir Econ 49, 1431–1462 (2015). https://doi.org/10.1007/s00181-015-0917-z
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DOI: https://doi.org/10.1007/s00181-015-0917-z