ISRN Probability and Statistics

Volume 2014 (2014), Article ID 864530, 7 pages

http://dx.doi.org/10.1155/2014/864530

Research Article

Average Derivative Estimation from Biased Data

Christophe Chesneau,¹ Maher Kachour,² and Fabien Navarro³

¹Département de Mathématiques, UFR de Sciences, LMNO, Université de Caen Basse-Normandie, 14032 Caen Cedex, France

²École Supérieure de Commerce IDRAC, 47 rue Sergent Michel Berthet CP 607, 69258 Lyon Cedex 09, France

³Laboratoire de Mathématiques Jean Leray, UFR Sciences et Techniques, Université de Nantes, 2 rue de la Houssiniére, BP 92208, F-44322 Nantes Cedex 3, France

Received 18 January 2014; Accepted 15 February 2014; Published 11 March 2014

Academic Editors: N. W. Hengartner, O. Pons, C. A. Tudor, and Y. Wu

Copyright © 2014 Christophe Chesneau et al. This is an open access article distributed under the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

Abstract.

We investigate the estimation of the density-weighted average derivative from biased data. An estimator integrating a plug-in approach and wavelet projections is constructed. We prove that it attains the parametric rate of convergence under the mean squared error.

1. Introduction

The standard density-weighted average derivative estimation problem is the following. We observe i.i.d. bivariate random variables defined on a probability space . Let be the unknown density function of , and let be the unknown regression function given by

The density-weighted average derivative is defined by

The estimation of is of interest in some econometric problems, especially in the context of estimation of coefficients in index models (see, e.g., Stoker [1, 2], Powell et al. [3], and Härdle and Stoker [4]). Among the popular approaches, there are the nonparametric techniques based on kernel estimators (see, e.g., Härdle and Stoker [4], Powell et al. [3], Härdle et al. [5], and Stoker [6]) or orthogonal series methods introduced in Rao [7]. Recently, Chesneau et al. [8] have developed an estimator based on a new plug-in approach and a wavelet series method. We refer to Antoniadis [9], Härdle et al. [10], and Vidakovic [11] for further details about wavelets and their applications in nonparametric statistics.

In this paper, we extend this estimation problem to the biased data. It is based on the “biased regression model” which is described as follows. We observe i.i.d. bivariate random variables defined on a probability space with the common density function:

where is a known positive function, is the density function of an unobserved bivariate random variable , and (which is an unknown real number). This model has potential applications in biology, economics, and many other fields. Important results on methods and applications can be found in, for example, Ahmad [12], Sköld [13], Cristóbal and Alcalá [14], Wu [15], Cristóbal and Alcalá [16], Cristóbal et al. [17], Ojeda et al. [18], Cabrera and Van Keilegom [19], and Chaubey et al. [20]. Wavelet methods related to this model can be found in Chesneau and Shirazi [21], Chaubey et al. [22], and Chaubey and Shirazi [23].

Let be the density of ; that is, , , and let be the unknown regression function given by

The density-weighted average derivative is defined by

We aim to estimate from . To reach this goal, we adapt the methodology of Chesneau et al. [8] to this problem and develop new technical arguments derived to those developed in Chesneau and Shirazi [21] for the estimation of (4). A new wavelet estimator is thus constructed. We prove that it attains the parametric rate of convergence under the mean squared error, showing the consistency of our estimator.

The paper is organized as follows. In Section 2, we introduce our wavelet methodology including our estimator. Additional assumptions on the model and our main theoretical result are set in Section 3. Finally, the proofs are postponed to Section 4.

2. Wavelet Methodology

In this section, after a brief description of the considered wavelet basis, we present our wavelet estimator of (5).

2.1. Compactly Supported Wavelet Basis

Let us consider the following set of functions:

For the purposes of this paper, we use the compactly supported wavelet bases on briefly described below.

Let be a fixed integer, and let and be the initial wavelet functions of the Daubechies wavelets (see, e.g., Mallat [24]). These functions have the features to be compactly supported and derivable.

Set

and . Then, with a specific treatments at the boundaries, there exists an integer such that the collection

is an orthonormal basis of .

Hence, a function can be expanded on as

where

Further details about wavelet basis can be found in, for example, Meyer [25], Cohen et al. [26], and Mallat [24].

2.2. Wavelet Estimator

Proposition 1 provides another expression of the density-weighted average derivative (5) in terms of wavelet coefficients.

Proposition 1. Let be given by (5). Suppose that , , , and . Then the density-weighted average derivative (5) can be expressed as

where

In view of Proposition 1, adapting the ideas of Chesneau et al. [8] and Chesneau and Shirazi [21] to our framework, we consider the following plug-in estimator for :

where

and is an integer which will be chosen a posteriori.

Proposition 2 provides some theoretical results explaining the constructions of the above estimators.

Proposition 2. Suppose that . Then

(i) (17) is an unbiased estimator for ;(ii) (15) and (16) are unbiased estimators for (12) and (13), respectively;(iii)under , (15) and (16) are unbiased estimators for (12) and (13), respectively.

3. Assumptions and Result

After the presentation of some additional assumptions on the model, we describe our main result on the asymptotic properties of (14).

3.1. Assumptions

We formulate the following assumptions on , , and .

(H1)The support of , denoted by , is compact. In order to fix the notations, we suppose that .(H2)There exists a constant such that

(H3)The function satisfies and there exists a constant such that

(H4)There exists a constant such that

(H5)There exist two constants and such that

Let , , and and be given by (13). We formulate the following assumptions on and .

(H6  ())There exists a constant such that

(H7  ())There exists a constant such that

Note that (H2)–(H5) are boundedness assumptions, whereas (H6  ()) and (H7   ()) are related to the smoothness of and represented by and . There exist deep connections between (H6 ()) and (H7 ()) and balls of Hölder spaces (see [10, Chapter 8]).

3.2. Main Result

The following theorem establishes the upper bound of the MSE of our estimator.

Theorem 3. Assume that (H1)–(H5), (H6 ()) with , and (H7 ()) with hold. Let be given by (5), and let be given by (14) with such that . Then there exists a constant such that

Theorem 3 proves that attains the parametric rate of convergence under the MSE. This implies the consistency of our estimator. This result provides a first theoretical aspect to the estimation of from biased data.

4. Proofs

4.1. On the Construction of

Proof of Proposition 1. We follow the approach of Chesneau et al. [8]. Using , , and an integration by parts, we obtain

Moreover,

(i)since , we can expand it on as (9):

 where and are (12),(ii)since , we can expand it on as (9):

 where and are (13).

Thanks to (25) and the orthonormality of on , we get

Proposition 1 is proved.

Proof of Proposition 2. (i) We have

(ii) Using the identical distribution of and the definition of (4), we obtain

Similarly, we prove that .

(iii) Using the identical distribution of , an integration by parts, and , we obtain

Similarly, we prove that .

This ends the proof of Proposition 2.

4.2. Proof of Some Intermediate Results

Proposition 4. Suppose that (H1)–(H5) hold. Let and be given by (13), and let and be given by (16) with such that . Then

(i)there exists a constant such that

(ii)there exists a constant such that

(iii)there exists a constant such that

These inequalities hold with in (15) instead of and in (12) instead of for .

Proof of Proposition 4. We use the following version of the Rosenthal inequality. The proof can be found in Rosenthal [27].

Lemma  5. Let be a positive integer, , and let be zero mean independent random variables such that . Then there exists a constant such that

(i)Note that

with

Since are i.i.d., we get that are also i.i.d.. Moreover, from Proposition 2, we have . Using (H5), for any , we have . Thus, Lemma  5 with yields

(ii)We have

By (H5), we have , , and by (H2) and (H3), . Hence, by the triangular inequality,

The elementary inequality, ,    , implies that

where

Upper bound for . Since are i.i.d., we get that are also i.i.d. Moreover, from Proposition 2, we have . Now, using the Hölder inequality, (H4), (H5) and , for any , observe that

Combining Lemma  5 with with the previous inequality, we obtain

Upper bound for . The point (i) yields

It follows from (41), (44), and (45) that

(iii)Similar arguments to the beginning of (ii) give

where

Upper bound for . Since are i.i.d., we get that are also i.i.d. Moreover, from Proposition 2, we have . Now, using the Hölder inequality, (H4), (H5), , and , for any , observe that

Owing to Lemma  5 with and the previous inequality, we obtain

Upper bound for . The point (i) yields

It follows from (47), (50), and (51) that

Proposition 4 is proved.

Proposition 6 below is a consequence of [8, Proposition  5.2] and the results of Proposition 4 above.

Proposition 6. (i) Suppose that (H1)–(H5), (H6 ()), and (H7 ()) hold. Let and be given by (13), and let and be given by (16) with such that . Then there exists a constant such that

(ii) Suppose that (H1)–(H5) hold. Let and be given by (12), and let and be given by (15). Then there exists a constant such that

4.3. Proof of the Main Result

Proof of Theorem 3. Using the intermediary results above, the proof follows the lines of [8, Theorem  5.1]. It follows from Proposition 1 and the elementary inequality, ,  , that

where

Upper bound for . Using the Cauchy-Schwarz inequality, the second point of Proposition 6, and , we obtain

Upper bound for . It follows from the Cauchy-Schwarz inequality, the first point of Proposition 6, , the elementary inequality, , , , and , that

Upper bound for . By (H6 ()) with , (H7 ()) with , and , we have

Putting (55), (57), (58), and (59) together, we obtain

This ends the proof of Theorem 3.

Conflict of Interests

The authors declare that there is no conflict of interests regarding the publication of this paper.

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