Improved Ratio Estimators in Adaptive Cluster Sampling
|
|
- Maude Quinn
- 6 years ago
- Views:
Transcription
1 Section on Survey Rearch Methods JSM 28 Improved Ratio Estimators in Adaptive Cluster Sampling Chang-Tai Chao Feng-Min Lin Tzu-Ching Chiang Abstract For better inference of the population quantity of intert, ratio timators are often recommended when certain auxiliary variabl are available. Two typ of ratio timators, modified for adaptive cluster sampling via transformed population and initial intersection probability approach, have been studied in Dryver and Chao 27. Unfortunately, none of them are a function of a minimal sufficient statistic, and therefore can be improved with Rao-blackwellization procedure. The purpose of this paper is to obtain new ratio timators that are not only more efficient than the original ratio timators proposed by Dryver and Chao, but simple to calculate. Additionally, explicit formulas for the approximated variance of the easy-to-compute timators are derived. Key Words: Auxiliary Variable, Ratio Estimator, Adaptive Cluster Sampling, Rao-blackwell Theorem 1. Introduction First proposed by Thompson 199, adaptive cluster sampling is an alternative to timate the population quantity of intert pecially under rare or clustered populations. The basic idea behind this approach is to take a small initial sample by some conventional digns, and then to increase thampling efficiency in the neighborhoods of the sampling units satisfying a condition previously defined. Under the dign-based inferential approach, although the usual unbiased timators in adaptive cluster sampling arimple to calculate, they do not necsarily utilize all the information provided by the rultant final sample. More efficient timators, the Rao-blackwell timators, can be obtained by using Rao-blackwell idea of conditioning on a minimum sufficient statistic. However, Thompson did not prent analytical exprsions for any of the Rao-blackwell timators but he computed the value of a Rao-blackwell timator by averaging the valu of the timator over all the initial sampl giving rise to the observed final sample. Clearly, the excsive number of calculations is required and hence it is sential for ordinary applications to achieve simply analytical exprsions. A few papers have given some analytical exprsions for the Rao-blackwell timators. For example, Salehi 1999 and Félix-Medina 2 have provided the colsed-form exprsions for the Rao-blackwell timators based on the modified Hansen-Hurwitz timator and the modified Horvitz-Thompson timator. In addition, Dryver and Thompson 25 have prented alternative mathematical formulas for the two Rao-blackwell timators derived by taking the expected value of the usual timators conditional on a sufficient statistic. The alternative Rao-blackwell timators may not as efficient as the Rao-blackwell timators obtained by taking the expected value of the usual timators conditional on a minimum sufficient statistic, but they are rather simple. The timators mentioned previously utilize the information provided by the population variable of intert only. Neverthels, to improve the quality of the timate in sampling survey, one not only depends on the the information of the primary variable, but reasonably needs to take relevant aspects of data into account. For many sampling survey situations, certain auxiliary variabl are often available and it is suggted to make use of the the auxiliary information for better inference. Ratio timation is a popular and widely used method to take advantage of the data from the variable of intert along with available auxiliary variabl. Although dign-biased, ratio timators are more efficient because they can give lower mean-square errors when sufficient correlations between the variable of intert and auxiliary variable exist. Moreover, the performanc of the ratio timators become more apparent as the correlations increase e.g., Lohr, Dryver and Chao 27 used auxiliary information into timators in adaptive cluster sampling to obtain ratio timators, which is a straightforward extension of the ratio timator under unequal probability sampling. None of those ratio timators, however, is a function of a minimum sufficient statistic and therefore can be improved with the approach similar to that the univariate timators derived.in this paper the Rao-blackwell ratio timators are derived by taking expected value of the ordinary ratio timators conditional on thamufficient statistic that Dryver and Thompson 25 utilized. However, the formulas for the Rao-blackwell ratio timators are not easily computed as those univariate timators proposed by Dryver and Thompson, but are exprsed as an average over the ratios for all edge units in the observed final sample where edge units are as defined in Section 2. The computation becom much more intensive as the number of the edge units turns large. In the intert of simplicity, we therefore further propose new, efficient, and easy-to-compute ratio Department of Statistics, National Cheng-Kung University Department of Statistics, National Cheng-Kung University Institute of Statistical Science, Academia Sinica 321
2 timators. Furthermore, explicit formulas for the approximated variance of the easy-to-compute ratio timators are derived. The paper is organized as follows. In Section 2, we briefly dcribe the ordinary timators in adaptive cluster sampling, including the dign-unbiased timators and ratio timators. In Section 3 are two typ of the new ratio timators proposed in this article. The Rao-blackwell ratio timators, derived with Rao-blackwellization procedure by conditioning on a sufficient statistic, are dcribed in Subsection 3.1; the derivation is given in Appendix A. In Subsection 3.2, the easy-to-compute ratio timators are illustrated and the formulas for their approximated variance are derived in Appendix B. Section 4 prents concluding comments. 2. Ordinary timators in adaptive cluster sampling In adaptive cluster sampling, an initial sample of units can belected by different typ of conventional probability sampling. In this article thimplt form of adaptive cluster sampling, an initial sample is selected by simple random sampling without replacement SRSWOR, will be considered Thompson, 199. Neverthels, the rult can be extended to other various typ of adaptive cluster sampling associated with different initial sampling digns. In this section, we will briefly dcribe the methodology and concepts involved in adaptive cluster sampling, and we will also introduce the notation used throughout this paper. The ordinary timators in adaptive cluster sampling have been proposed, including the dign-unbiased and ratio timators, are addrsed in this section as well. 2.1 Dign-unbiased timators in adaptive cluster sampling In a basic sampling view, population is a finitet of units consisting of N units with labels 1,..., N, denoted as u = {u 1,..., u N }. Associated with each unit i, the valu of the population variable of intert is denoted as y i. Through this article, the population quantity of intert to be timated is the population mean of the y s, that is, µ y = N y i /N. 1 i=1 In adaptive cluster sampling, thampling procedure is selecting a small initial sample by some conventional digns, and whenever the variable of intert of a unit in thmall initial samplatisfi a given condition C, units in some predefined neighborhood will be included into thample and observed. C is typically a function of the population variable of intert based on the options and the experience of experts for various populations. Neighborhood can be defined by social or institutional relationships between units. The most prevalent, by far, is the neighborhood consisting of the unit itself and the four adjacent units, left, right, top and bottom. In this paper, consider an initial sampl = u 1,..., u n of size is selected from u via SRSWOR. If any of the units in s satisfy C, for example, y i c where c is a constant, their rpective neighborhoods are added to thample and observed. Furthermore, if any added units satisfy C, the units in the neighborhood are added to thample and observed as well, and so on. This procedure is iterated until no new units satisfy. Thet formed by the original unit in s and together with the units added as a consequence of selecting u i is called a cluster. The units adaptively selected but not meet C are called edge units. A cluster minus the edge units is called a network. Any unit not satisfying C is, by definition, a network of size 1. Let A k be the network containing unit i and m k denote the number of units in A k. Then the average of the y valu in the kth network is w yk = 1 m k i A k y i. 2 The population mean of the y s can be written in terms of networks and denote as µ y = K w y k /N, where K is the number of the distinct networks in the population Ordinary timators Section on Survey Rearch Methods JSM 28 Adaptive cluster sampling is a case of Unequal Probability Dign if networks are considered as sampling units. Thompson 199 developed two unbiased timators based on the modifications of the Hansen-Hurwitz and Horvitz- Thompson timators. With this dign, unfortunately, neither the draw-by-draw selection probability, nor the inclusion probability can be determined from the data for the units that do not satisfy C and are not included in the initial sample. Consequently, observations that do not satisfy C are ignore if they are not included in the initial sample. 3211
3 One of the unbiased timators in adaptive cluster sampling, the modified Hansen-Hurwitz timator, is based on the initial draw-by-draw selection probabiliti. Let I. denote an indicator function equalling 1 when the exprsion inside is true and otherwise. The number of units selected from the kth network in the initial sample is n k = i A k Ii s. 3 The modified Hansen-Hurwitz timator and its variance are where κ is the number of distinct networks intersected by the initial sample and varˆµ y hh = ˆµ y hh = 1 κ n k w yk, 4 N n NnN 1 Another unbiased timator using the partial inclusion probabiliti is ˆµ y ht = 1 N K m k w yk µ 2. 5 κ u yk, 6 [ ] N mk N where u yk = m k w yk and = 1 / is the initial intersection probability of the kth network. The joint initial intersection probabiliti is [ N mk h = 1 The variance of ˆµ y ht is Rao-Blackwell timators Section on Survey Rearch Methods JSM 28 varˆµ y hh = 1 N 2 K N mh K h=1 ] N mk m h N /. 7 αkh α h u yk u yh. 8 α h Under the dign-based inferential approach, the ordinary timators do not necsarily utilize all the information provided by the rultant final sample. Only the edge units in the initial sample are incorporated when computing them. The Rao-blackwell theorem can be used to improve the efficiency of the ordinary timators sincome variability can be reduced by making use of the observations of the edge units which are not in the initial sample. Dryver and Thompson 25 utilized a sufficient statistic instead of the minimum sufficient statistic, and obtained the easy-to-compute Rao-blackwell timators which were developed by considering only how many edge units were initial selected, but not which on. In this section, only the timators and their corrponding varianc will be introduced. More detailed proofs and dcriptions can be found in Dryver and Thompson s paper. A statistic d is defined as d = {i, y i, f i, j, y j ; i s c, j s c }. 9 For unit i, f i is the number of tim that the network to which unit i belongs is intersected by the initial sample. The union of a core part s c and the remaining part s c is the final sampl. The core part s c consists of all the distinct units in thample which satisfy the condition. The remaining part s c is thet of all the distinct units in thample for which the condition is not met. Thtatistic d is sufficient for µ so applying by the Rao-blackwell theorem to ˆµ y hh and ˆµ y ht, the easy-to-compute Rao-blackwell timators ˆµ y hh and ˆµ y ht are arrived. One of the Rao-blackwell timators, ˆµ y hh, is defined by where ˆµ y hh = E ˆµ y hh D = d = 1 κ n k w y n k. 1 w yk w y k = ȳ e = e i y i i s, if e i =,, if e i =
4 Section on Survey Rearch Methods JSM 28 Note ȳ e is the average y value for thample edge units in the final sample and is the number of sample edge units in s. For the ith unit in thample, the indicator variable e i is defined as { 1, if i do not meet the condition but is in the neighborhood, e i =, otherwise. 12 Additionally, for those units which are not in s, e i =. The variance of ˆµ y hh is varˆµ y hh = N n K m k w yk µ 2 NnN 1 1 n 2 Pd e s d D y 2 i 1 1 y i y j e 2 s ȳ 2 e, 13 where Pd is the probability that D = d and is the number of units picked in s. The other timators ˆµ y ht is defined by ˆµ y ht = E ˆµ y ht D = d = 1 N κ m k w yk 14 and has variance varˆµ y ht = 1 K K αkh α h N 2 u yk u yh α h=1 k α h 1 n 2 Pd e s y 2 i 1 e d D s 1 y i y j e 2 s ȳ 2 e Ordinary ratio timators in adaptive cluster sampling In many applied survey situations of adaptive cluster sampling, auxiliary variable is often collected together with the population variable of intert. Dryver and Chao 27 utilized the auxiliary information into the timation, and proposed two ratio timators in adaptive cluster sampling by taking advantage of the correlation between the variable of intert and the auxiliary variable. In this section the two ordinary ratio timators and their varianc will be briefly dcribed. Let µ x be the population mean of the auxiliary variable x. The ordinary ratio timator related to the modified Hansen-Hurwitz timator is ˆµ r hh = ˆµ y hh ˆµ x hh µ x, 16 where ˆµ x hh is the modified Hansen-Hurwitz timator for µ x. The approximated variance of ˆµ r hh is Avarˆµ r hh = N n NnN 1 K m k w yk Rw xk 2, 17 where R is the population ratio between w yk and w xk. The other ratio timator of µ y can be constructed based on the modified Horvitz-Thompson timator and is defined by ˆµ r ht = ˆµ y ht ˆµ x ht µ x, 18 where ˆµ y ht and ˆµ x ht are the modified Horvitz-Thompson timators for µ y and µ x, rpectively. The approximated variance is the variance of the modified Horvitz-Thompson timator of the variable u k = u y k Ru xk. Avarˆµ r ht = 1 N 2 K h=1 K u ku h αkh α h α h
5 3. New ratio timators in adaptive cluster sampling In subsection 3.1 the real Rao-blackwell ratio timators, derived with Rao-blackwellization procedure by conditioning on thufficient statistic d, are arrived. The derivation of the Rao-blackwell ratio timators is given in Appendix A. The formulas for them are not as easy as those univariate timators proposed by Dryver and Thompson 25, and the computation becom much more intensive as the number of the edge units turns large. In the intert of simplicity, we therefore further propose two efficient and easy-to-compute ratio timators and the formulas for them are prented in Subsection 3.2. Furthermore, explicit formulas for the approximated variance of the easy-to-compute ratio timators are derived and the derivation is given in Appendix B. 3.1 Rao-Blackwell ratio timators Mentioned in the previous section, thtatistic d is sufficient for µ. So the Rao-blackwell ratio timators ˆµ r hh and ˆµ r ht are able to be arrived at by applying the Rao-blackwell theorem to ˆµ r hh and ˆµ r ht. The Rao-blackwell ratio timator ˆµ r hh is defined by ˆµ r hh = E ˆµ r hh D = d. 2 The timator is not easily computed as shown by the formula κ ˆµ r hh = e n kw yk 1 e i e i y i s i Ψ k e κ s n kw xk 1 µ x. 21 e i e i x i The other Rao-blackwell ratio timator ˆµ r ht is not easily computed as well and the formula is given as ˆµ r ht =E ˆµ r ht D = d 22 κ u yk 1 N e iy i = κ e i n u xk 1 e i n N e µ x. 23 ix i The proofs that equations 2 and 21, and 22 and 23 are rpectively equivalent are given in Appendix A. 3.2 Easy-to-compute ratio timators The formulas for the real Rao-blackwell ratio timators are too complicated to be calculated in practice. To simplify the calculation, we therefore further construct other improved timators via a ratio of the Rao-blackwellized univariate timators conditioning on thufficient statistic d. The new ratio timators are very easily computed and their approximated varianc are ls than or equal to the varianc of the original ratio timators proposed by Dryver and Chao 27. The two easy-to-compute ratio timators and their varianc will be briefly dcribed. One of the easy-to-compute timators ˆµ r hh is defined to be κ ˆµ r hh = ˆµ n kw yk 1 e i ȳ e y hh i Ψ ˆµ µ x = k κ x hh n kw xk 1 µ x, 24 e i x e where ˆµ y hh and ˆµ x hh are the Hansen-Hurwitz type Rao-blackwell timator for µ y and µ x. x e is the average x value for thample edge units in the final sample. The approximated variance of ˆµ r hh is Avar ˆµ r hh = Avar ˆµr hh 1 n The other easy-to-compute timator ˆµ r ht is Section on Survey Rearch Methods JSM 28 ˆµ r ht = ˆµ y ht ˆµ µ x = x ht Pd d D κ κ y i Rx i 2 y i Rx i y j Rx j e 2 s ȳ e R x e 2. u yk 1 1 u xk e i n e i n N ȳe N x e 25 µ x
6 Section on Survey Rearch Methods JSM 28 The approximated variance of ˆµ r ht is Avar ˆµ r ht = Avar ˆµr ht 1 n 2 Pd e s y i Rx i 2 d D 1 y i Rx i y j Rx j e 2 s 1 ȳ e R x e Conclusions In order to make the bt use of survey data in adaptive cluster sampling, we discuss how to utilize auxiliary information into timation. Improving ratio timators with Rao-blackwellization is the main object in this study. We derive the real Rao-blackwell ratio timators by taking expected value of the ordinary ratio timators conditional on thamufficient statistic that Dryver and Thompson 25 utilized. However, the formulas for the Raoblackwell ratio timators are too complicated to be calculated in practice. In the intert of simplicity, we therefore further construct other improved timators via a ratio of the Rao-blackwellized univariate timators conditioning on thufficient statistic. Furthermore, we have been able to obtain the explicit formulas for the approximated variance of those easy-to-compute ratio timators and therefore guarantee their approximated mean square errors are lower than those of the unimproved ratio timators proposed by Dryver and Chao 27. From the model-based perspective population valu are considered to be random variabl, and reprent just one outcome of many possible outcom under a specific model. This probability model can be constructed by detailed surveys or experience and may offer more efficient inferenc than dign-based approach. However, validity of inference depends on the correctns of this assumed model. We did not discuss the inferenc via model-based perspective in this rearch. Similar study under the model-based point of view will be invtigated in the future. Appendix A. Derivation of the Rao-blackwell ratio timators We only derive ˆµ r hh and leave the derivation of ˆµ r ht to the reader because the approach to obtain the formula for ˆµ r ht is not much different from the approach for ˆµ r hh. Let ˆµ r hh s reprent ˆµ r hh as a function of the initial sampl. Let S be a random variable taking on valu from thamplpace S and PS = s D = d is the probability of that initial sample given d. Thus the Hansen-Hurwitz type Rao-blackwell ratio timator is ˆµ r hh = E ˆµ r hh D = d = s S ˆµ r hh s PS = s D = d. The conditional probability PS = s D = d can be written as I{gs = d }/L, where I{.} is an indicator function and L = s I{gs S = d } is the total number of combinations compatible with d. And out of the L combinations any single unit appears 1 1 L. Thus the timator can be written as ˆµ r hh = 1 I{gs = d }ˆµ r hh L s s S 1 = 1 ˆµ r hh s s S = κ n kw yk 1 e i e i y i κ n kw xk 1 e i e i x i µ x. 3215
7 B. Derivation of the approximated variance of the easy-to-compute ratio timators The improved ratio timator is hence the timator can be written ˆµ r = ˆµ y ˆµ µ x = ˆRµx ; x ˆµ r = ˆµ y ˆRµx ˆµ x. The first term in Taylor s formula, expanding about the point µ x, µ giv the approximation Consequently, The approximation for the variance is Avar ˆµ r Hence, Avar ˆµ r =var Eˆµy Rˆµ x D =var ˆµ y Rˆµ x E varˆµ y Rˆµ x D ˆµ r ˆµ y Rµ x ˆµ x. ˆµ r µ ˆµ y Rµ x ˆµ x µ = ˆµ y Rˆµ x. = E ˆµ y Rˆµ 2 x = var ˆµ y Rˆµ x = var Eˆµy Rˆµ x D. =Avar ˆµ r E ˆµ y Rˆµ x ˆµ y Rˆµ x 2 =Avar ˆµ r 1 Pd n 2 Ld I{gs = d } 2 y i Rx i ȳ e R x e d D s S i s,e i =1 =Avar ˆµ r 1 Pd n 2 Ld I{gs = d } y i Rx i 2 e 2 s ȳ e R x e 2 d D s S i s,e i =1 =Avar ˆµ r 1 Pd n 2 Ld I{gs = d } d D s S y i Rx i 2 y i Rx i y j Rx j e 2 s ȳ e R x e 2 i s,e i =1 i s,e i =1 j i =Avar ˆµ r 1 n 2 Pd d D y i Rx i 2 2 =Avar ˆµ r 1 n 2 Pd d D e s y i Rx i Section on Survey Rearch Methods JSM 28 REFERENCES y i Rx i y j Rx j e 2 s ȳ e R x e 2 y i Rx i y j Rx j e 2 s ȳ e R x e 2 Dryver, A. L., and Thompson, S. K. 25, Improved unbiased timators in adaptive cluster sampling, Journal of the Royal Statistical Society B, 67, Dryver, A. L., and Chao, C. T. 27, Ratio timators in adaptive cluster sampling, Environmetrics, 18, Félix Medina, M. H. 2, Analytical exprsions for Rao-Blackwell timators in adaptive cluster sampling, Journal of Statistical Planning and Inference, 84, Salehi, M. M. 1999, Rao-Blackwell versions of the Hansen-Hurwitz and Horvitz-Thompson timators in adaptive cluster sampling, Ecological and Environmental Statistics, 6, Thompson, S. K.199, Adaptive cluster sampling, Journal of the American Statistical Association, 77, Thompson, S. K., and Seber, G.A.F. 1996, Adaptive Sampling, New York: Wiley. 3216
1 The continuous time limit
Derivative Securities, Courant Institute, Fall 2008 http://www.math.nyu.edu/faculty/goodman/teaching/derivsec08/index.html Jonathan Goodman and Keith Lewis Supplementary notes and comments, Section 3 1
More informationChapter 7 presents the beginning of inferential statistics. The two major activities of inferential statistics are
Chapter 7 presents the beginning of inferential statistics. Concept: Inferential Statistics The two major activities of inferential statistics are 1 to use sample data to estimate values of population
More informationNorth West Los Angeles Average Price of Coffee in Licensed Establishments
North West Los Angeles Average Price of Coffee in Licensed Establishments By Courtney Engel, Natasha Ericta and Ray Luo Statistics 201A Sample Project Professor Xu December 14, 2006 1 1 Background and
More information2 Modeling Credit Risk
2 Modeling Credit Risk In this chapter we present some simple approaches to measure credit risk. We start in Section 2.1 with a short overview of the standardized approach of the Basel framework for banking
More informationStratified Sampling in Monte Carlo Simulation: Motivation, Design, and Sampling Error
South Texas Project Risk- Informed GSI- 191 Evaluation Stratified Sampling in Monte Carlo Simulation: Motivation, Design, and Sampling Error Document: STP- RIGSI191- ARAI.03 Revision: 1 Date: September
More informationAnnual risk measures and related statistics
Annual risk measures and related statistics Arno E. Weber, CIPM Applied paper No. 2017-01 August 2017 Annual risk measures and related statistics Arno E. Weber, CIPM 1,2 Applied paper No. 2017-01 August
More informationInterval estimation. September 29, Outline Basic ideas Sampling variation and CLT Interval estimation using X More general problems
Interval estimation September 29, 2017 STAT 151 Class 7 Slide 1 Outline of Topics 1 Basic ideas 2 Sampling variation and CLT 3 Interval estimation using X 4 More general problems STAT 151 Class 7 Slide
More informationChapter 4 Variability
Chapter 4 Variability PowerPoint Lecture Slides Essentials of Statistics for the Behavioral Sciences Seventh Edition by Frederick J Gravetter and Larry B. Wallnau Chapter 4 Learning Outcomes 1 2 3 4 5
More informationMaximum Likelihood Estimation
Maximum Likelihood Estimation The likelihood and log-likelihood functions are the basis for deriving estimators for parameters, given data. While the shapes of these two functions are different, they have
More informationarxiv: v1 [q-fin.rm] 13 Dec 2016
arxiv:1612.04126v1 [q-fin.rm] 13 Dec 2016 The hierarchical generalized linear model and the bootstrap estimator of the error of prediction of loss reserves in a non-life insurance company Alicja Wolny-Dominiak
More informationChapter 5. Statistical inference for Parametric Models
Chapter 5. Statistical inference for Parametric Models Outline Overview Parameter estimation Method of moments How good are method of moments estimates? Interval estimation Statistical Inference for Parametric
More informationCalibration Estimation under Non-response and Missing Values in Auxiliary Information
WORKING PAPER 2/2015 Calibration Estimation under Non-response and Missing Values in Auxiliary Information Thomas Laitila and Lisha Wang Statistics ISSN 1403-0586 http://www.oru.se/institutioner/handelshogskolan-vid-orebro-universitet/forskning/publikationer/working-papers/
More informationDefinition 9.1 A point estimate is any function T (X 1,..., X n ) of a random sample. We often write an estimator of the parameter θ as ˆθ.
9 Point estimation 9.1 Rationale behind point estimation When sampling from a population described by a pdf f(x θ) or probability function P [X = x θ] knowledge of θ gives knowledge of the entire population.
More informationLecture Notes 6. Assume F belongs to a family of distributions, (e.g. F is Normal), indexed by some parameter θ.
Sufficient Statistics Lecture Notes 6 Sufficiency Data reduction in terms of a particular statistic can be thought of as a partition of the sample space X. Definition T is sufficient for θ if the conditional
More informationECON FINANCIAL ECONOMICS
ECON 337901 FINANCIAL ECONOMICS Peter Ireland Boston College Fall 2017 These lecture notes by Peter Ireland are licensed under a Creative Commons Attribution-NonCommerical-ShareAlike 4.0 International
More informationOPTIMAL PORTFOLIO CONTROL WITH TRADING STRATEGIES OF FINITE
Proceedings of the 44th IEEE Conference on Decision and Control, and the European Control Conference 005 Seville, Spain, December 1-15, 005 WeA11.6 OPTIMAL PORTFOLIO CONTROL WITH TRADING STRATEGIES OF
More informationA Convenient Way of Generating Normal Random Variables Using Generalized Exponential Distribution
A Convenient Way of Generating Normal Random Variables Using Generalized Exponential Distribution Debasis Kundu 1, Rameshwar D. Gupta 2 & Anubhav Manglick 1 Abstract In this paper we propose a very convenient
More informationSharpe Ratio over investment Horizon
Sharpe Ratio over investment Horizon Ziemowit Bednarek, Pratish Patel and Cyrus Ramezani December 8, 2014 ABSTRACT Both building blocks of the Sharpe ratio the expected return and the expected volatility
More informationAustralian Journal of Basic and Applied Sciences. Conditional Maximum Likelihood Estimation For Survival Function Using Cox Model
AENSI Journals Australian Journal of Basic and Applied Sciences Journal home page: wwwajbaswebcom Conditional Maximum Likelihood Estimation For Survival Function Using Cox Model Khawla Mustafa Sadiq University
More informationCalibration approach estimators in stratified sampling
Statistics & Probability Letters 77 (2007) 99 103 www.elsevier.com/locate/stapro Calibration approach estimators in stratified sampling Jong-Min Kim a,, Engin A. Sungur a, Tae-Young Heo b a Division of
More informationModule 4: Point Estimation Statistics (OA3102)
Module 4: Point Estimation Statistics (OA3102) Professor Ron Fricker Naval Postgraduate School Monterey, California Reading assignment: WM&S chapter 8.1-8.4 Revision: 1-12 1 Goals for this Module Define
More informationAppendix A (Pornprasertmanit & Little, in press) Mathematical Proof
Appendix A (Pornprasertmanit & Little, in press) Mathematical Proof Definition We begin by defining notations that are needed for later sections. First, we define moment as the mean of a random variable
More informationThe extent to which they accumulate productive assets.
Technology Transfer Our analysis of the neoclassical growth model illustrated that growth theory predicts significant differences in per capita income across countries due to : The extent to which they
More informationPARAMETRIC AND NON-PARAMETRIC BOOTSTRAP: A SIMULATION STUDY FOR A LINEAR REGRESSION WITH RESIDUALS FROM A MIXTURE OF LAPLACE DISTRIBUTIONS
PARAMETRIC AND NON-PARAMETRIC BOOTSTRAP: A SIMULATION STUDY FOR A LINEAR REGRESSION WITH RESIDUALS FROM A MIXTURE OF LAPLACE DISTRIBUTIONS Melfi Alrasheedi School of Business, King Faisal University, Saudi
More informationEdgeworth Binomial Trees
Mark Rubinstein Paul Stephens Professor of Applied Investment Analysis University of California, Berkeley a version published in the Journal of Derivatives (Spring 1998) Abstract This paper develops a
More informationEstimation of a parametric function associated with the lognormal distribution 1
Communications in Statistics Theory and Methods Estimation of a parametric function associated with the lognormal distribution Jiangtao Gou a,b and Ajit C. Tamhane c, a Department of Mathematics and Statistics,
More informationSTOCHASTIC CALCULUS AND BLACK-SCHOLES MODEL
STOCHASTIC CALCULUS AND BLACK-SCHOLES MODEL YOUNGGEUN YOO Abstract. Ito s lemma is often used in Ito calculus to find the differentials of a stochastic process that depends on time. This paper will introduce
More informationStatistical Methodology. A note on a two-sample T test with one variance unknown
Statistical Methodology 8 (0) 58 534 Contents lists available at SciVerse ScienceDirect Statistical Methodology journal homepage: www.elsevier.com/locate/stamet A note on a two-sample T test with one variance
More informationChapter 7. Inferences about Population Variances
Chapter 7. Inferences about Population Variances Introduction () The variability of a population s values is as important as the population mean. Hypothetical distribution of E. coli concentrations from
More informationOptimizing Portfolios
Optimizing Portfolios An Undergraduate Introduction to Financial Mathematics J. Robert Buchanan 2010 Introduction Investors may wish to adjust the allocation of financial resources including a mixture
More informationThe Two-Sample Independent Sample t Test
Department of Psychology and Human Development Vanderbilt University 1 Introduction 2 3 The General Formula The Equal-n Formula 4 5 6 Independence Normality Homogeneity of Variances 7 Non-Normality Unequal
More informationThe Complexity of GARCH Option Pricing Models
JOURNAL OF INFORMATION SCIENCE AND ENGINEERING 8, 689-704 (01) The Complexity of GARCH Option Pricing Models YING-CHIE CHEN +, YUH-DAUH LYUU AND KUO-WEI WEN + Department of Finance Department of Computer
More informationSharpe Ratio Practice Note
Sharpe Ratio Practice Note Geng Deng, PhD, FRM Tim Dulaney, PhD Craig McCann, PhD, CFA Securities Litigation and Consulting Group, Inc. 3998 Fair Ridge Drive, Suite 250, Fairfax, VA 22033 June 26, 2012
More informationRisk Decomposition for Portfolio Simulations
Risk Decomposition for Portfolio Simulations Marco Marchioro www.statpro.com Version 1.0 April 2010 Abstract We describe a method to compute the decomposition of portfolio risk in additive asset components
More informationEcon 424/CFRM 462 Portfolio Risk Budgeting
Econ 424/CFRM 462 Portfolio Risk Budgeting Eric Zivot August 14, 2014 Portfolio Risk Budgeting Idea: Additively decompose a measure of portfolio risk into contributions from the individual assets in the
More informationFast Computation of the Economic Capital, the Value at Risk and the Greeks of a Loan Portfolio in the Gaussian Factor Model
arxiv:math/0507082v2 [math.st] 8 Jul 2005 Fast Computation of the Economic Capital, the Value at Risk and the Greeks of a Loan Portfolio in the Gaussian Factor Model Pavel Okunev Department of Mathematics
More informationMS-E2114 Investment Science Lecture 5: Mean-variance portfolio theory
MS-E2114 Investment Science Lecture 5: Mean-variance portfolio theory A. Salo, T. Seeve Systems Analysis Laboratory Department of System Analysis and Mathematics Aalto University, School of Science Overview
More informationWeek 2 Quantitative Analysis of Financial Markets Hypothesis Testing and Confidence Intervals
Week 2 Quantitative Analysis of Financial Markets Hypothesis Testing and Confidence Intervals Christopher Ting http://www.mysmu.edu/faculty/christophert/ Christopher Ting : christopherting@smu.edu.sg :
More informationEFFICIENT ESTIMATORS FOR THE POPULATION MEAN
Hacettepe Journal of Mathematics and Statistics Volume 38) 009), 17 5 EFFICIENT ESTIMATORS FOR THE POPULATION MEAN Nursel Koyuncu and Cem Kadılar Received 31:11 :008 : Accepted 19 :03 :009 Abstract M.
More informationCPSC 540: Machine Learning
CPSC 540: Machine Learning Monte Carlo Methods Mark Schmidt University of British Columbia Winter 2019 Last Time: Markov Chains We can use Markov chains for density estimation, d p(x) = p(x 1 ) p(x }{{}
More informationProbability & Statistics
Probability & Statistics BITS Pilani K K Birla Goa Campus Dr. Jajati Keshari Sahoo Department of Mathematics Statistics Descriptive statistics Inferential statistics /38 Inferential Statistics 1. Involves:
More informationMTH6154 Financial Mathematics I Stochastic Interest Rates
MTH6154 Financial Mathematics I Stochastic Interest Rates Contents 4 Stochastic Interest Rates 45 4.1 Fixed Interest Rate Model............................ 45 4.2 Varying Interest Rate Model...........................
More informationReview of key points about estimators
Review of key points about estimators Populations can be at least partially described by population parameters Population parameters include: mean, proportion, variance, etc. Because populations are often
More informationComparison of design-based sample mean estimate with an estimate under re-sampling-based multiple imputations
Comparison of design-based sample mean estimate with an estimate under re-sampling-based multiple imputations Recai Yucel 1 Introduction This section introduces the general notation used throughout this
More informationThe Binomial Lattice Model for Stocks: Introduction to Option Pricing
1/33 The Binomial Lattice Model for Stocks: Introduction to Option Pricing Professor Karl Sigman Columbia University Dept. IEOR New York City USA 2/33 Outline The Binomial Lattice Model (BLM) as a Model
More information8.1 Estimation of the Mean and Proportion
8.1 Estimation of the Mean and Proportion Statistical inference enables us to make judgments about a population on the basis of sample information. The mean, standard deviation, and proportions of a population
More informationDESCENDANTS IN HEAP ORDERED TREES OR A TRIUMPH OF COMPUTER ALGEBRA
DESCENDANTS IN HEAP ORDERED TREES OR A TRIUMPH OF COMPUTER ALGEBRA Helmut Prodinger Institut für Algebra und Diskrete Mathematik Technical University of Vienna Wiedner Hauptstrasse 8 0 A-00 Vienna, Austria
More informationChapter 7 - Lecture 1 General concepts and criteria
Chapter 7 - Lecture 1 General concepts and criteria January 29th, 2010 Best estimator Mean Square error Unbiased estimators Example Unbiased estimators not unique Special case MVUE Bootstrap General Question
More informationSimple Formulas to Option Pricing and Hedging in the Black-Scholes Model
Simple Formulas to Option Pricing and Hedging in the Black-Scholes Model Paolo PIANCA DEPARTMENT OF APPLIED MATHEMATICS University Ca Foscari of Venice pianca@unive.it http://caronte.dma.unive.it/ pianca/
More informationTechnical Report: CES-497 A summary for the Brock and Hommes Heterogeneous beliefs and routes to chaos in a simple asset pricing model 1998 JEDC paper
Technical Report: CES-497 A summary for the Brock and Hommes Heterogeneous beliefs and routes to chaos in a simple asset pricing model 1998 JEDC paper Michael Kampouridis, Shu-Heng Chen, Edward P.K. Tsang
More informationCONSISTENCY AMONG TRADING DESKS
CONSISTENCY AMONG TRADING DESKS David Heath 1 and Hyejin Ku 2 1 Department of Mathematical Sciences, Carnegie Mellon University, Pittsburgh, PA, USA, email:heath@andrew.cmu.edu 2 Department of Mathematics
More informationMore On λ κ closed sets in generalized topological spaces
Journal of Algorithms and Computation journal homepage: http://jac.ut.ac.ir More On λ κ closed sets in generalized topological spaces R. Jamunarani, 1, P. Jeyanthi 2 and M. Velrajan 3 1,2 Research Center,
More informationدرس هفتم یادگیري ماشین. (Machine Learning) دانشگاه فردوسی مشهد دانشکده مهندسی رضا منصفی
یادگیري ماشین توزیع هاي نمونه و تخمین نقطه اي پارامترها Sampling Distributions and Point Estimation of Parameter (Machine Learning) دانشگاه فردوسی مشهد دانشکده مهندسی رضا منصفی درس هفتم 1 Outline Introduction
More informationLecture 22. Survey Sampling: an Overview
Math 408 - Mathematical Statistics Lecture 22. Survey Sampling: an Overview March 25, 2013 Konstantin Zuev (USC) Math 408, Lecture 22 March 25, 2013 1 / 16 Survey Sampling: What and Why In surveys sampling
More informationCPSC 540: Machine Learning
CPSC 540: Machine Learning Monte Carlo Methods Mark Schmidt University of British Columbia Winter 2018 Last Time: Markov Chains We can use Markov chains for density estimation, p(x) = p(x 1 ) }{{} d p(x
More informationBudget Setting Strategies for the Company s Divisions
Budget Setting Strategies for the Company s Divisions Menachem Berg Ruud Brekelmans Anja De Waegenaere November 14, 1997 Abstract The paper deals with the issue of budget setting to the divisions of a
More informationChapter 5. Continuous Random Variables and Probability Distributions. 5.1 Continuous Random Variables
Chapter 5 Continuous Random Variables and Probability Distributions 5.1 Continuous Random Variables 1 2CHAPTER 5. CONTINUOUS RANDOM VARIABLES AND PROBABILITY DISTRIBUTIONS Probability Distributions Probability
More informationGamma. The finite-difference formula for gamma is
Gamma The finite-difference formula for gamma is [ P (S + ɛ) 2 P (S) + P (S ɛ) e rτ E ɛ 2 ]. For a correlation option with multiple underlying assets, the finite-difference formula for the cross gammas
More informationExtend the ideas of Kan and Zhou paper on Optimal Portfolio Construction under parameter uncertainty
Extend the ideas of Kan and Zhou paper on Optimal Portfolio Construction under parameter uncertainty George Photiou Lincoln College University of Oxford A dissertation submitted in partial fulfilment for
More informationModeling Portfolios that Contain Risky Assets Stochastic Models I: One Risky Asset
Modeling Portfolios that Contain Risky Assets Stochastic Models I: One Risky Asset C. David Levermore University of Maryland, College Park Math 420: Mathematical Modeling March 25, 2014 version c 2014
More informationThe Binomial Model. Chapter 3
Chapter 3 The Binomial Model In Chapter 1 the linear derivatives were considered. They were priced with static replication and payo tables. For the non-linear derivatives in Chapter 2 this will not work
More informationAN APPROACH TO THE STUDY OF MULTIPLE STATE MODELS. BY H. R. WATERS, M.A., D. Phil., 1. INTRODUCTION
AN APPROACH TO THE STUDY OF MULTIPLE STATE MODELS BY H. R. WATERS, M.A., D. Phil., F.I.A. 1. INTRODUCTION 1.1. MULTIPLE state life tables can be considered a natural generalization of multiple decrement
More informationYoungrok Lee and Jaesung Lee
orean J. Math. 3 015, No. 1, pp. 81 91 http://dx.doi.org/10.11568/kjm.015.3.1.81 LOCAL VOLATILITY FOR QUANTO OPTION PRICES WITH STOCHASTIC INTEREST RATES Youngrok Lee and Jaesung Lee Abstract. This paper
More informationReview of key points about estimators
Review of key points about estimators Populations can be at least partially described by population parameters Population parameters include: mean, proportion, variance, etc. Because populations are often
More informationA relation on 132-avoiding permutation patterns
Discrete Mathematics and Theoretical Computer Science DMTCS vol. VOL, 205, 285 302 A relation on 32-avoiding permutation patterns Natalie Aisbett School of Mathematics and Statistics, University of Sydney,
More informationThe Multinomial Logit Model Revisited: A Semiparametric Approach in Discrete Choice Analysis
The Multinomial Logit Model Revisited: A Semiparametric Approach in Discrete Choice Analysis Dr. Baibing Li, Loughborough University Wednesday, 02 February 2011-16:00 Location: Room 610, Skempton (Civil
More informationMATH3075/3975 FINANCIAL MATHEMATICS TUTORIAL PROBLEMS
MATH307/37 FINANCIAL MATHEMATICS TUTORIAL PROBLEMS School of Mathematics and Statistics Semester, 04 Tutorial problems should be used to test your mathematical skills and understanding of the lecture material.
More informationIEOR E4703: Monte-Carlo Simulation
IEOR E4703: Monte-Carlo Simulation Simulation Efficiency and an Introduction to Variance Reduction Methods Martin Haugh Department of Industrial Engineering and Operations Research Columbia University
More informationPortfolio Sharpening
Portfolio Sharpening Patrick Burns 21st September 2003 Abstract We explore the effective gain or loss in alpha from the point of view of the investor due to the volatility of a fund and its correlations
More informationA NEW POINT ESTIMATOR FOR THE MEDIAN OF GAMMA DISTRIBUTION
Banneheka, B.M.S.G., Ekanayake, G.E.M.U.P.D. Viyodaya Journal of Science, 009. Vol 4. pp. 95-03 A NEW POINT ESTIMATOR FOR THE MEDIAN OF GAMMA DISTRIBUTION B.M.S.G. Banneheka Department of Statistics and
More informationInformation aggregation for timing decision making.
MPRA Munich Personal RePEc Archive Information aggregation for timing decision making. Esteban Colla De-Robertis Universidad Panamericana - Campus México, Escuela de Ciencias Económicas y Empresariales
More informationThe Optimization Process: An example of portfolio optimization
ISyE 6669: Deterministic Optimization The Optimization Process: An example of portfolio optimization Shabbir Ahmed Fall 2002 1 Introduction Optimization can be roughly defined as a quantitative approach
More informationMathematics in Finance
Mathematics in Finance Steven E. Shreve Department of Mathematical Sciences Carnegie Mellon University Pittsburgh, PA 15213 USA shreve@andrew.cmu.edu A Talk in the Series Probability in Science and Industry
More informationA. 11 B. 15 C. 19 D. 23 E. 27. Solution. Let us write s for the policy year. Then the mortality rate during year s is q 30+s 1.
Solutions to the Spring 213 Course MLC Examination by Krzysztof Ostaszewski, http://wwwkrzysionet, krzysio@krzysionet Copyright 213 by Krzysztof Ostaszewski All rights reserved No reproduction in any form
More informationMethods and Models of Loss Reserving Based on Run Off Triangles: A Unifying Survey
Methods and Models of Loss Reserving Based on Run Off Triangles: A Unifying Survey By Klaus D Schmidt Lehrstuhl für Versicherungsmathematik Technische Universität Dresden Abstract The present paper provides
More informationFinancial Risk Forecasting Chapter 9 Extreme Value Theory
Financial Risk Forecasting Chapter 9 Extreme Value Theory Jon Danielsson 2017 London School of Economics To accompany Financial Risk Forecasting www.financialriskforecasting.com Published by Wiley 2011
More informationVARIABILITY: Range Variance Standard Deviation
VARIABILITY: Range Variance Standard Deviation Measures of Variability Describe the extent to which scores in a distribution differ from each other. Distance Between the Locations of Scores in Three Distributions
More informationBayesian Linear Model: Gory Details
Bayesian Linear Model: Gory Details Pubh7440 Notes By Sudipto Banerjee Let y y i ] n i be an n vector of independent observations on a dependent variable (or response) from n experimental units. Associated
More informationMSc Financial Engineering CHRISTMAS ASSIGNMENT: MERTON S JUMP-DIFFUSION MODEL. To be handed in by monday January 28, 2013
MSc Financial Engineering 2012-13 CHRISTMAS ASSIGNMENT: MERTON S JUMP-DIFFUSION MODEL To be handed in by monday January 28, 2013 Department EMS, Birkbeck Introduction The assignment consists of Reading
More informationEstimating the Parameters of Closed Skew-Normal Distribution Under LINEX Loss Function
Australian Journal of Basic Applied Sciences, 5(7): 92-98, 2011 ISSN 1991-8178 Estimating the Parameters of Closed Skew-Normal Distribution Under LINEX Loss Function 1 N. Abbasi, 1 N. Saffari, 2 M. Salehi
More informationNote on Cost of Capital
DUKE UNIVERSITY, FUQUA SCHOOL OF BUSINESS ACCOUNTG 512F: FUNDAMENTALS OF FINANCIAL ANALYSIS Note on Cost of Capital For the course, you should concentrate on the CAPM and the weighted average cost of capital.
More informationOptimal Production-Inventory Policy under Energy Buy-Back Program
The inth International Symposium on Operations Research and Its Applications (ISORA 10) Chengdu-Jiuzhaigou, China, August 19 23, 2010 Copyright 2010 ORSC & APORC, pp. 526 532 Optimal Production-Inventory
More informationGeneralized Modified Ratio Type Estimator for Estimation of Population Variance
Sri Lankan Journal of Applied Statistics, Vol (16-1) Generalized Modified Ratio Type Estimator for Estimation of Population Variance J. Subramani* Department of Statistics, Pondicherry University, Puducherry,
More informationChapter 7: Estimation Sections
1 / 31 : Estimation Sections 7.1 Statistical Inference Bayesian Methods: 7.2 Prior and Posterior Distributions 7.3 Conjugate Prior Distributions 7.4 Bayes Estimators Frequentist Methods: 7.5 Maximum Likelihood
More informationKey Objectives. Module 2: The Logic of Statistical Inference. Z-scores. SGSB Workshop: Using Statistical Data to Make Decisions
SGSB Workshop: Using Statistical Data to Make Decisions Module 2: The Logic of Statistical Inference Dr. Tom Ilvento January 2006 Dr. Mugdim Pašić Key Objectives Understand the logic of statistical inference
More informationThe Delta Method. j =.
The Delta Method Often one has one or more MLEs ( 3 and their estimated, conditional sampling variancecovariance matrix. However, there is interest in some function of these estimates. The question is,
More informationIntroduction to Probability Theory and Stochastic Processes for Finance Lecture Notes
Introduction to Probability Theory and Stochastic Processes for Finance Lecture Notes Fabio Trojani Department of Economics, University of St. Gallen, Switzerland Correspondence address: Fabio Trojani,
More informationInferences on Correlation Coefficients of Bivariate Log-normal Distributions
Inferences on Correlation Coefficients of Bivariate Log-normal Distributions Guoyi Zhang 1 and Zhongxue Chen 2 Abstract This article considers inference on correlation coefficients of bivariate log-normal
More informationValue of Flexibility in Managing R&D Projects Revisited
Value of Flexibility in Managing R&D Projects Revisited Leonardo P. Santiago & Pirooz Vakili November 2004 Abstract In this paper we consider the question of whether an increase in uncertainty increases
More informationElif Özge Özdamar T Reinforcement Learning - Theory and Applications February 14, 2006
On the convergence of Q-learning Elif Özge Özdamar elif.ozdamar@helsinki.fi T-61.6020 Reinforcement Learning - Theory and Applications February 14, 2006 the covergence of stochastic iterative algorithms
More informationInference of Several Log-normal Distributions
Inference of Several Log-normal Distributions Guoyi Zhang 1 and Bose Falk 2 Abstract This research considers several log-normal distributions when variances are heteroscedastic and group sizes are unequal.
More informationThe Binomial Lattice Model for Stocks: Introduction to Option Pricing
1/27 The Binomial Lattice Model for Stocks: Introduction to Option Pricing Professor Karl Sigman Columbia University Dept. IEOR New York City USA 2/27 Outline The Binomial Lattice Model (BLM) as a Model
More informationComparison of MINQUE and Simple Estimate of the Error Variance in the General Linear Models
Acta Mathematicae Applicatae Sinica, English Series Vol. 19, No. 1 (003) 13 18 Comparison of MINQUE and Simple Estimate of the Error Variance in the General Linear Models Song-gui Wang 1,Mi-xiaWu,Wei-qingMa
More informationChapter 7: Estimation Sections
1 / 40 Chapter 7: Estimation Sections 7.1 Statistical Inference Bayesian Methods: Chapter 7 7.2 Prior and Posterior Distributions 7.3 Conjugate Prior Distributions 7.4 Bayes Estimators Frequentist Methods:
More information- 1 - **** d(lns) = (µ (1/2)σ 2 )dt + σdw t
- 1 - **** These answers indicate the solutions to the 2014 exam questions. Obviously you should plot graphs where I have simply described the key features. It is important when plotting graphs to label
More informationF A S C I C U L I M A T H E M A T I C I
F A S C I C U L I M A T H E M A T I C I Nr 38 27 Piotr P luciennik A MODIFIED CORRADO-MILLER IMPLIED VOLATILITY ESTIMATOR Abstract. The implied volatility, i.e. volatility calculated on the basis of option
More informationA RIDGE REGRESSION ESTIMATION APPROACH WHEN MULTICOLLINEARITY IS PRESENT
Fundamental Journal of Applied Sciences Vol. 1, Issue 1, 016, Pages 19-3 This paper is available online at http://www.frdint.com/ Published online February 18, 016 A RIDGE REGRESSION ESTIMATION APPROACH
More informationNovember 2012 Course MLC Examination, Problem No. 1 For two lives, (80) and (90), with independent future lifetimes, you are given: k p 80+k
Solutions to the November 202 Course MLC Examination by Krzysztof Ostaszewski, http://www.krzysio.net, krzysio@krzysio.net Copyright 202 by Krzysztof Ostaszewski All rights reserved. No reproduction in
More informationGlobal Currency Hedging
Global Currency Hedging JOHN Y. CAMPBELL, KARINE SERFATY-DE MEDEIROS, and LUIS M. VICEIRA ABSTRACT Over the period 1975 to 2005, the U.S. dollar (particularly in relation to the Canadian dollar), the euro,
More informationEstimation after Model Selection
Estimation after Model Selection Vanja M. Dukić Department of Health Studies University of Chicago E-Mail: vanja@uchicago.edu Edsel A. Peña* Department of Statistics University of South Carolina E-Mail:
More information