Weighted censored quantile regression

Section 1. Introduction

In quantile regression (Koenker, 2005), the conditional quantiles of the response variable for a given set of predictor variables are modelled. The regression parameters are estimated by minimizing a check loss function at a specific quantile, τ , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaeqiXdqNaai ilaaaa@386C@ instead of the square loss function as in the standard linear regression. A quantile regression model based on properly selected quantiles could provide a global assessment of the covariate effects on the response, which is often ignored by the standard linear regression model. Recently, censored quantile regression has been studied extensively. Powell (1984) introduced the least absolute deviation (LAD) estimator, also called the median regression model for the left censored survival data, using the censored Tobit model (Tobin, 1958). Powell (1986) generalized the LAD estimation to any quantile.

Portnoy (2003) introduced a censored quantile regression model under random censoring as a generalization of the Kaplan-Meier estimator recursively using the Kaplan-Meier estimator (Kaplan and Meier, 1958). Peng and Huang (2008) developed a censored quantile regression model based on the Nelson-Aalen estimator using counting processes and martingale theory. In survival analysis setup, for the i th MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamyAamaaCa aaleqabaGaaeiDaiaabIgaaaaaaa@38F4@ ( i = 1 , 2 , , n ) MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaWaaeWaaeaaca WGPbGaeyypa0JaaGymaiaacYcacaaMe8UaaGOmaiaacYcacaaMe8Ua eSOjGSKaaiilaiaaysW7caWGUbaacaGLOaGaayzkaaaaaa@43B7@ subject, let T i MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamivamaaBa aaleaacaWGPbaabeaaaaa@37EA@ be the logarithm of the failure time, C i MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaam4qamaaBa aaleaacaWGPbaabeaaaaa@37D9@ the logarithm of right censoring time, X i MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCiwamaaBa aaleaacaWGPbaabeaaaaa@37F2@ the p MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamiCaaaa@36EC@ -vector covariate and let Y i = min ( T i , C i ) MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamywamaaBa aaleaacaWGPbaabeaakiabg2da9iGac2gacaGGPbGaaiOBamaabmaa baGaamivamaaBaaaleaacaWGPbaabeaakiaacYcacaaMe8Uaam4qam aaBaaaleaacaWGPbaabeaaaOGaayjkaiaawMcaaaaa@4380@ be the logarithm of the survival time. For a given quantile, τ , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaeqiXdqNaai ilaaaa@386C@ the regression coefficients, β ( τ ) , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCOSdmaabm aabaGaeqiXdqhacaGLOaGaayzkaaGaaiilaaaa@3B33@ can be estimated as

β ^ ( τ ) = arg min β p i = 1 n ρ τ ( Y i min { C i , X i β } ) , ( 1.1 ) MathType@MTEF@5@5@+= feaagKart1ev2aaatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGabCOSdyaaja WaaeWaaeaacqaHepaDaiaawIcacaGLPaaacqGH9aqpdaWfqaqaaiGa cggacaGGYbGaai4zaiGac2gacaGGPbGaaiOBaaWcbaGaeqOSdiMaey icI4SaaGjcVprr1ngBPrMrYf2A0vNCaeHbfv3ySLgzGyKCHTgD1jha iuaacqWFCeIudaahaaadbeqaaiaadchaaaaaleqaaOWaaabCaeaacq aHbpGCdaWgaaWcbaGaeqiXdqhabeaaaeaacaWGPbGaeyypa0JaaGym aaqaaiaad6gaa0GaeyyeIuoakmaabmaabaGaamywamaaBaaaleaaca WGPbaabeaakiabgkHiTiGac2gacaGGPbGaaiOBamaacmaabaGaam4q amaaBaaaleaacaWGPbaabeaakiaacYcacaaMe8UaaCiwamaaDaaale aacaWGPbaabaqefqvyO9wBHbacgaGaa4hPdaaakiaahk7aaiaawUha caGL9baaaiaawIcacaGLPaaacaGGSaGaaGzbVlaaywW7caaMf8UaaG zbVlaaywW7caGGOaGaaGymaiaac6cacaaIXaGaaiykaaaa@7D46@

where ρ τ ( u ) = u [ τ I ( u < 0 ) ] , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaeqyWdi3aaS baaSqaaiabes8a0bqabaGcdaqadaqaaiaadwhaaiaawIcacaGLPaaa cqGH9aqpcaWG1bWaamWaaeaacqaHepaDcqGHsisltuuDJXwAK1uy0H MmaeHbfv3ySLgzG0uy0HgiuD3BaGqbaiab=Hi8jnaabmaabaGaamyD aiabgYda8iaaicdaaiaawIcacaGLPaaaaiaawUfacaGLDbaacaGGSa aaaa@53B3@ is the check loss function.

In many studies, we may have some information about the target population from previous studies. This is common in survey sampling since surveys are carried out repeatedly with similar objectives. For example, in survey sampling, information about the population mean and variance could be available from previous surveys or records. The information of the parameters as well as type of relationship, distributional assumptions, etc. also could be considered as auxiliary information available for analysis. The auxiliary information could be effectively used to improve the efficiency of the statistical inference (Kuk and Mak, 1989; Rao, Kovar and Mantel, 1990; Chen and Qin, 1993). The idea used in this paper can be easily extendable in survey sampling to arrive efficient parameter estimates by making use of the information available from previous surveys.

Consider a known relationship between the survival time, Y MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamywaaaa@36D5@ (or the failure time, T ) MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamivaiaacM caaaa@377D@ and a set of covariates X , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCiwaiaacY caaaa@3788@ as Y = f ( X ; θ ) , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamywaiabg2 da9iaadAgadaqadaqaaiaahIfacaGG7aGaaGjbVlaahI7aaiaawIca caGLPaaacaGGSaaaaa@3F70@ where θ MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCiUdaaa@373B@ is the parameter of interest. The knowledge about this relationship can be treated as auxiliary information. In a more general case, the auxiliary information can be expressed as E { g ( Z ; θ ) } = 0 MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamyramaacm aabaGaam4zamaabmaabaGaaCOwaiaacUdacaaMe8UaaCiUdaGaayjk aiaawMcaaaGaay5Eaiaaw2haaiabg2da9iaaicdaaaa@419A@ for some d MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamizaaaa@36E0@ -dimensional parameter, θ R d , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCiUdiabgI GiolaadkfadaahaaWcbeqaaiaadsgaaaGccaGGSaaaaa@3B66@ where Z MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCOwaaaa@36DA@ is the observed data from the present study and g ( Z ; θ ) R q , MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaam4zamaabm aabaGaaCOwaiaacUdacaaMe8UaaCiUdaGaayjkaiaawMcaaiabgIGi olaadkfadaahaaWcbeqaaiaadghaaaGccaGGSaaaaa@4117@ some function with q d . MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaamyCaiabgw MiZkaadsgacaGGUaaaaa@3A4E@ The parameter, θ MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaaCiUdaaa@373B@ could be unknown, but can be estimated using the information available from previous studies.

Chen and Qin (1993) introduced the use of auxiliary information to improve the efficiency of estimators in the context of survey sampling using empirical likelihood (Owen, 1988, 2001). Li and Wang (2003) accommodated the auxiliary information to the censored linear regression model using empirical likelihood by defining a synthetic variable (Koul, Susarla and Ryzin, 1981). Fang, Li, Lu and Qin (2013) proposed the effective use of auxiliary information in the linear regression model with right censored data using empirical likelihood, by utilizing the Buckley-James (Buckley and James, 1979) estimating equation. Tang and Leng (2012) introduced an empirical likelihood based linear quantile regression model using auxiliary information.

In this paper, we propose an empirical likelihood (EL) based approach to accommodate auxiliary information to the censored quantile regression. EL is a non-parametric likelihood approach proposed by Owen (1988, 2001), which has similar properties of parametric likelihood. We utilize the EL based data driven probabilities as the weights by using the estimating function, g ( Z ; θ ) MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaam4zamaabm aabaGaaCOwaiaacUdacaaMe8UaaCiUdaGaayjkaiaawMcaaaaa@3CDF@ and incorporate those weights into the censored quantile regression model. The resulted weighted censored quantile regression parameter β ( τ ) MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaeqOSdi2aae WaaeaacqaHepaDaiaawIcacaGLPaaaaaa@3AE6@ can be estimated as

β ^ ( τ ) = arg min β p i = 1 n ω i ρ τ ( Y i min { C i , X i β } ) , ( 1.2 ) MathType@MTEF@5@5@+= feaagKart1ev2aaatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGabCOSdyaaja WaaeWaaeaacqaHepaDaiaawIcacaGLPaaacqGH9aqpdaWfqaqaaiGa cggacaGGYbGaai4zaiaaysW7ciGGTbGaaiyAaiaac6gaaSqaaiabek 7aIjabgIGiolaayIW7tuuDJXwAKzKCHTgD1jharyqr1ngBPrgigjxy RrxDYbacfaGae8hhHi1aaWbaaWqabeaacaWGWbaaaaWcbeaakmaaqa habaGaeqyYdC3aaSbaaSqaaiaadMgaaeqaaOGaeqyWdi3aaSbaaSqa aiabes8a0bqabaaabaGaamyAaiabg2da9iaaigdaaeaacaWGUbaani abggHiLdGcdaqadaqaaiaadMfadaWgaaWcbaGaamyAaaqabaGccqGH sislciGGTbGaaiyAaiaac6gadaGadaqaaiaadoeadaWgaaWcbaGaam yAaaqabaGccaGGSaGaaGjbVlaahIfadaqhaaWcbaGaamyAaaqaaerb ufgAV1wyaGGbaiaa+r6aaaGccaWHYoaacaGL7bGaayzFaaaacaGLOa GaayzkaaGaaiilaiaaywW7caaMf8UaaGzbVlaaywW7caaMf8Uaaiik aiaaigdacaGGUaGaaGOmaiaacMcaaaa@81C5@

where ω i s MathType@MTEF@5@5@+= feaagKart1ev2aqatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbuLwBLn hiov2DGi1BTfMBaeXatLxBI9gBaerbd9wDYLwzYbItLDharqqtubsr 4rNCHbGeaGqiFu0Je9sqqrpepC0xbbL8F4rqqrpgpC0xc9LqFf0xc9 qqpeuf0xe9q8qiYRWFGCk9vi=dbbf9v8Gq0db9qqpm0dXdHqpq0=vr 0=vr0=edbaqaaeGaciGaaiaabeqaamaabaabaaGcbaGaeqyYdC3aaS baaSqaaiaadMgaaeqaaGqaaOGaa8xgGiaa=nhaaaa@3A9F@ are the weights. We propose to use the EL based data driven probabilities as the weights. Our simulation results show that the EL based weighted censored quantile regression performs more efficiently than the standard linear censored quantile regression.

The rest of the paper is organized as follows. In Section 2, we present the estimation procedure of the EL based data driven probabilities. In Section 3, we introduce the EL based weighted censored quantile regression and investigate the asymptotic properties of the estimators. In Section 4, performance analysis of the proposed method is conducted using the simulations. The application to the north central cancer treatment lung cancer data is also presented as an illustration. Our conclusions are given in Section 5.


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