New robust inference for predictive regressions

Transcription

1 New robust inference for predictive regressions Anton Skrobotov Russian Academy of National Economy and Public Administration and Innopolis University based on joint work with Rustam Ibragimov and Jihyun Kim Research supported by a grant from Russian Science Foundaton (Project No ) The IAAE grant is gratefully acknowledged Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

2 Motivation Motivation Endogeneity Consider the following predictive regression for t = 1,..., T, where x t is some covariate. y t = α + x t 1 + u t, (1) x t = ρx t 1 + v t, (2) Our purpose to test the null hypothesis of no predictability of y t (e.g., stock returns). In other words, we want to test H 0 : = 0. If the process x t be stationary then we estimate by OLS and construct t-ratio, t( ˆ OLS ), which converges to standard Normal distribution. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

3 Motivation Motivation Endogeneity Consider the following predictive regression for t = 1,..., T, where x t is some covariate. y t = α + x t 1 + u t, (3) x t = ρx t 1 + v t, (4) If, howewer, x t is (near) non-stationary, ( x t = 1 c ) x t 1 + v t, T we can use standard Normal inference only if the u t and v t are uncorrelated. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

4 Motivation Motivation Endogeneity Consider the following predictive regression y t = α + x t 1 + u t, (5) x t = ρx t 1 + v t, (6) More presicely, let ξ i = (u i, v i ), and (appropriately normalizing) u t converges to a bivariate Wiener process ([ [rt ]] 1 [rt ] i=1 ξ i B(s) = (U(r), V (r)) ) with covariance matrix ( ) ω 2 Ω = y ω xy ω xy It can be shown that t( ˆ OLS ) P + Q, where Q is normal and P is function of Ornstein-Uhlenbeck process (near-unit root distributions). If ω xy = 0, then P vanishes from the limiting distribution, so that t( ˆ OLS ) N(0, 1). Otherwise, there are serious size distortions. ω 2 x Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

5 Motivation Motivation Non-stationary volatility Consider the following predictive regression y t = α + x t 1 + u t, (7) x t = ρx t 1 + v t, (8) u t = σ t 1 ε t, where ε t is MDS w.r.t. ltration F t 1, s.t. E(ε 2 t F t 1 ) = 1. Therefore, E(u y,2 t F t 1 ) = σ 2 t 1. The volatility process σ t may be (nearly) non-stationary: σ t = ω(z t ), where z t is (near) unit root process, or σ t = ω(t/t ) (xed or random), or σ t = ω(z t / T ) (see Choi et al., 2016). Then the limiting distribution of t( ˆ OLS ) is non-normal, even when there is no endogeneity (no dependence between u t and v t ). Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

6 Choi et al., 2016 The robust test for no predictability First assume α = 0 in predictive regression. Also assume MDS assumption of u t (no non-stationary volatility). Choi et al., 2016 proposed so called Cauchy estimator of, ( T ) 1 T ˆ T = x t 1 sgn(x t 1 )y t, (9) t=1 where sgn( ) is a sign function such that sign(x) = 1 for x 0 and sign(x) = 1 for x < 0. Extention 1: α 0 recursive de-meaning (the limiting distribution is the same). Extention 2: u t follows non-stationary volatility assumption Time Change in continuous time framework (the limiting distribution is the same). t=1 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

7 Choi et al., 2016 The robust test for no predictability It can be shown that under the null hypothesis of = 0, 1 T T t=1 u t 1 0 σ(s)dw (s) = d MN(0, Q), where Q is some (random) variance depending on the volatility process (Q = 1 0 σ(s)2 ds), and therefore 1 T T t=1 sgn(x t 1 )y t = 1 T T t=1 sgn(x t 1 )u t Therefore, the numerator of the Cauchy estimator, ˆδ T := 1 0 σ(s)dw (s) = d MN(0, Q). T sgn(x t 1 )y t (10) t=1 has approximately mixed normal distribution with mean zero and variance Q T. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

8 Choi et al., 2016 Brief review of t-statistic based robust inference Bakirov and Szekely (2005), Ibragimov and Mueller (2010, 2016): Usual small sample t-test of level α 5%: conservative for independent heterogeneous Gaussian observations (not α = 10%) X j N(µ, σ 2 j ), j = 1,..., q: H 0 : µ = 0 vs. H 1 : µ 0 t-statistic t = q X s X X = q 1 q j=1 X j, s 2 X = (q 1) 1 q j=1 (X j X) 2 cv q (α) = critical value of T q 1 : P ( T q 1 > cv q (α)) = α P ( t > cv(α) H 0 ) P ( t > cv(α) H 0, σ 2 1 = = σ 2 q) = α Holds under heavy tails, mixtures of normals (stable, Student-t) Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

9 Choi et al., 2016 Brief review of t-statistic based robust inference Regression: Assume data can be classied in a nite number q of groups that allow asymptotically independent normal inference about the (scalar) parameter of interest, so that ˆ j idn(, vj 2 ) for j = 1,..., q. Time series example: Divide data into q = 4 consecutive blocks, and estimate the model 4 times. Treat ˆ j as observations for the usual t-statistic, and reject a 5% level test if t-statistic is larger than usual critical value for q 1 degrees of freedom. Results in valid inference by small sample result. Exploits information ˆ j idn(, vj 2 ) in an ecient way. Does not rely on single asymptotic model of sampling variability for estimated standard deviation Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

10 Monte Carlo Results Same design as in Andrews (1991): Linear Regression, 5 regressors, 4 nonconstant regressors are independent draws from stationary Gaussian AR(1), as are the disturbances, + heteroskedasticity. T = 128, 5% level test about coefficient of one nonconstant regressor. t-statistic (q) ˆω 2 QA ˆω2 PW ˆω 2 BT (b) ρ Size ρ Size Adjusted Power

11 Choi et al., 2016 The robust test for no predictability It can be shown that under the null hypothesis of = 0, 1 T T t=1 u t 1 0 σ(s)dw (s) = d MN(0, Q), where Q is some (random) variance depending on the volatility process (Q = 1 0 σ(s)2 ds), and therefore 1 T T t=1 sgn(x t 1 )y t = 1 T T t=1 sgn(x t 1 )u t Therefore, the numerator of the Cauchy estimator, ˆδ T := 1 0 σ(s)dw (s) = d MN(0, Q). T sgn(x t 1 )y t (11) t=1 has approximately mixed normal distribution with mean zero and variance Q T. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

12 Choi et al., 2016 The robust test for no predictability Consider partition of the data into q 2 approximately equal groups G j = {s : (j 1)T/q < s jt/q}, j = 1,..., q. Then we have q subsamples for which we calculate q numerators of Cauchy estimator of (11), ˆδ T,j, j = 1,..., q. Therefore, we have (ˆδ T,1, ˆδ T,2,..., ˆδ T,q ) N (0, diag(t Q 1,..., T Q q )) (12) under assumption about asymptotically independence of δ T,j. Following Ibragimov and Muller (2010), asymptotic Gaussianity then allow us to construct asymptotically valid (conservative) test of level α 83 of H 0 : = 0 against H 1 : 0 by rejecting H 0 when t IV, exceed (1 α/2) percentile of Student t-distribution with q 1 degrees of freedom, where t IV, is constructed as t IV, = q ˆδ/sˆδ (13) with ˆδ = q 1 q j=1 ˆδ T,j and sˆδ = (q 1) 1 q j=1 (ˆδT,j ˆδ) 2. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

13 Choi et al., 2016 The robust test for no predictability Consider partition of the data into q 2 approximately equal groups G j = {s : (j 1)T/q < s jt/q}, j = 1,..., q. Then we have q subsamples for which we calculate q numerators of Cauchy estimator of (11), ˆδ T,j, j = 1,..., q. Therefore, we have (ˆδ T,1, ˆδ T,2,..., ˆδ T,q ) N (0, diag(t Q 1,..., T Q q )) (12) under assumption about asymptotically independence of δ T,j. Following Ibragimov and Muller (2010), asymptotic Gaussianity then allow us to construct asymptotically valid (conservative) test of level α 83 of H 0 : = 0 against H 1 : 0 by rejecting H 0 when t IV, exceed (1 α/2) percentile of Student t-distribution with q 1 degrees of freedom, where t IV, is constructed as t IV, = q ˆδ/sˆδ (13) with ˆδ = q 1 q j=1 ˆδ T,j and sˆδ = (q 1) 1 q j=1 (ˆδT,j ˆδ) 2. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

14 We use continuous time model as in Choi et al. (2016) dy t = T X tdt + du t, (14) dx t = κ T X tdt + σ t dv t, (15) ) du t = σ t (dw t + xλ(dt, dx), (16) where V t and W t are Brownian motion with correlation coecient and α = 0. The continuous data are generated to b eobserved at δ-intervals over T years, so that there are δt daily obserations. See Choi et al. (2016). Compare with Bonferroni Q-test of Campbell and Yogo, 2006 (BQ) and restricted likelihood ratio test of Chen and Deo, 2009 (RLRT) R Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

15 Volatility process: Model CNST. Constant volatility : σ 2 t = σ 2 0, σ 0 = 1. Model SB. Structural break in volatility : σ 0 + (σ 1 σ 0 )I(t 4T/5) with σ 0 = 1 and σ 1 = 4. Model GBM. Geometric Brownian motion: dσt 2 = 1 ω 2 2 T σ2 t dt + ω2 T σt 2 dz t, Z t is Brownian motion which correlated with W t with correlation coecient - and ω is set to be 9. Model RS. Regime switching : σ t = σ 0 (1 s t ) + σ 1 s t, where s t be a homogeneous Markov process indicating the current state of the world which is independent on both Y t and X t with transition matrix with the state space {0, 1} P t = ( ) + ( ) ( exp λ ) T t with λ = 60, σ 0 = 1 and σ 1 = 4. s t is initialized by its invariant distribution. Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

16 Finite Sample Property Constant volatility: σ t = σ Table: Sizes of tests κ = 0 κ = 5 κ = CNST OLS BQ RLRT Cauchy RT q= q= q= q= Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

17 Single break in vlatility: σ t = 1 for t [0, 4T/5] and σ t = 4 for t [4T/5, T ] Table: Sizes of tests κ = 0 κ = 5 κ = SB OLS BQ RLRT Cauchy RT q= q= q= q= Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

18 Regime switching model: σ t = σ 0 (1 s t ) + σ 1 s t, s t is homogeneous Markov process independent of both Y and X Table: Sizes of tests κ = 0 κ = 5 κ = RS OLS BQ RLRT Cauchy RT q= q= q= q= Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

19 Geometric Brownian motion: dσ 2 t = ω2 2 σ2 t dt + ωσ 2 t dz t, Z t BM, correlated with W (with -), ω = 9/ T. Table: Sizes of tests κ = 0 κ = 5 κ = GBM OLS BQ RLRT Cauchy RT q= q= q= q= Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

20 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) CNST, κ = 0, T = 5 (b) CNST, κ = 5, T = (c) CNST, κ = 20, T = 5 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

21 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) CNST, κ = 0, T = 50 (b) CNST, κ = 5, T = (c) CNST, κ = 20, T = 50 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

22 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) SB, κ = 0, T = 5 (b) SB, κ = 5, T = (c) SB, κ = 20, T = 5 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

23 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) SB, κ = 0, T = 50 (b) SB, κ = 5, T = (c) SB, κ = 20, T = 50 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

24 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) GBM, κ = 0, T = 5 (b) GBM, κ = 5, T = (c) GBM, κ = 20, T = 5 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

25 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) GBM, κ = 0, T = 50 (b) GBM, κ = 5, T = (c) GBM, κ = 20, T = 50 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

26 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) RS, κ = 0, T = 5 (b) RS, κ = 5, T = (c) RS, κ = 20, T = 5 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

27 OLS:,Bonf.Q:,RLRT:,CauchyRT:,q=4:,q=8:,q=12:,q=16: (a) RS, κ = 0, T = 50 (b) RS, κ = 5, T = (c) RS, κ = 20, T = 50 Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

28 Concluding remarks New approach to robust inference in predictive regression Based on instrumental variable estimator (Cauchy estimator) which allows the endogeneity between variables The inference then based on splitting the sample and obtaining robust Student t-test The obtaining approach is robust to a wide class of errors: dependence, heterockedasticity, nonstationary volatility and heavy tails Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27

29 Thank you for attention! Anton Skrobotov (RANEPA, Innopolis) New robust inference for predictive regressions June 28, / 27