University of Tartu DISTRIBUTIONS in FINANCIAL MATHEMATICS (MTMS.02.023)
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5.1 Convergence in Distribution
556: MATHEMATICAL STATISTICS I CHAPTER 5: STOCHASTIC CONVERGENCE The following definitions are stated in terms of scalar random variables, but extend naturally to vector random variables defined on the same probability space with measure P . Forp example, some results 2 are stated in terms of the Euclidean distance in one dimension jXn − Xj = (Xn − X) , or for se- > quences of k-dimensional random variables Xn = (Xn1;:::;Xnk) , 0 1 1=2 Xk @ 2A kXn − Xk = (Xnj − Xj) : j=1 5.1 Convergence in Distribution Consider a sequence of random variables X1;X2;::: and a corresponding sequence of cdfs, FX1 ;FX2 ;::: ≤ so that for n = 1; 2; :: FXn (x) =P[Xn x] : Suppose that there exists a cdf, FX , such that for all x at which FX is continuous, lim FX (x) = FX (x): n−!1 n Then X1;:::;Xn converges in distribution to random variable X with cdf FX , denoted d Xn −! X and FX is the limiting distribution. Convergence of a sequence of mgfs or cfs also indicates conver- gence in distribution, that is, if for all t at which MX (t) is defined, if as n −! 1, we have −! () −!d MXi (t) MX (t) Xn X: Definition : DEGENERATE DISTRIBUTIONS The sequence of random variables X1;:::;Xn converges in distribution to constant c if the limiting d distribution of X1;:::;Xn is degenerate at c, that is, Xn −! X and P [X = c] = 1, so that { 0 x < c F (x) = X 1 x ≥ c Interpretation: A special case of convergence in distribution occurs when the limiting distribution is discrete, with the probability mass function only being non-zero at a single value, that is, if the limiting random variable is X, then P [X = c] = 1 and zero otherwise. -
Estimation of Α-Stable Sub-Gaussian Distributions for Asset Returns
Estimation of α-Stable Sub-Gaussian Distributions for Asset Returns Sebastian Kring, Svetlozar T. Rachev, Markus Hochst¨ otter¨ , Frank J. Fabozzi Sebastian Kring Institute of Econometrics, Statistics and Mathematical Finance School of Economics and Business Engineering University of Karlsruhe Postfach 6980, 76128, Karlsruhe, Germany E-mail: [email protected] Svetlozar T. Rachev Chair-Professor, Chair of Econometrics, Statistics and Mathematical Finance School of Economics and Business Engineering University of Karlsruhe Postfach 6980, 76128 Karlsruhe, Germany and Department of Statistics and Applied Probability University of California, Santa Barbara CA 93106-3110, USA E-mail: [email protected] Markus Hochst¨ otter¨ Institute of Econometrics, Statistics and Mathematical Finance School of Economics and Business Engineering University of Karlsruhe Postfach 6980, 76128, Karlsruhe, Germany Frank J. Fabozzi Professor in the Practice of Finance School of Management Yale University New Haven, CT USA 1 Abstract Fitting multivariate α-stable distributions to data is still not feasible in higher dimensions since the (non-parametric) spectral measure of the characteristic func- tion is extremely difficult to estimate in dimensions higher than 2. This was shown by Chen and Rachev (1995) and Nolan, Panorska and McCulloch (1996). α-stable sub-Gaussian distributions are a particular (parametric) subclass of the multivariate α-stable distributions. We present and extend a method based on Nolan (2005) to estimate the dispersion matrix of an α-stable sub-Gaussian dis- tribution and estimate the tail index α of the distribution. In particular, we de- velop an estimator for the off-diagonal entries of the dispersion matrix that has statistical properties superior to the normal off-diagonal estimator based on the covariation. -
Parameter Specification of the Beta Distribution and Its Dirichlet
%HWD'LVWULEXWLRQVDQG,WV$SSOLFDWLRQV 3DUDPHWHU6SHFLILFDWLRQRIWKH%HWD 'LVWULEXWLRQDQGLWV'LULFKOHW([WHQVLRQV 8WLOL]LQJ4XDQWLOHV -5HQpYDQ'RUSDQG7KRPDV$0D]]XFKL (Submitted January 2003, Revised March 2003) I. INTRODUCTION.................................................................................................... 1 II. SPECIFICATION OF PRIOR BETA PARAMETERS..............................................5 A. Basic Properties of the Beta Distribution...............................................................6 B. Solving for the Beta Prior Parameters...................................................................8 C. Design of a Numerical Procedure........................................................................12 III. SPECIFICATION OF PRIOR DIRICHLET PARAMETERS................................. 17 A. Basic Properties of the Dirichlet Distribution...................................................... 18 B. Solving for the Dirichlet prior parameters...........................................................20 IV. SPECIFICATION OF ORDERED DIRICHLET PARAMETERS...........................22 A. Properties of the Ordered Dirichlet Distribution................................................. 23 B. Solving for the Ordered Dirichlet Prior Parameters............................................ 25 C. Transforming the Ordered Dirichlet Distribution and Numerical Stability ......... 27 V. CONCLUSIONS........................................................................................................ 31 APPENDIX................................................................................................................... -
Severity Models - Special Families of Distributions
Severity Models - Special Families of Distributions Sections 5.3-5.4 Stat 477 - Loss Models Sections 5.3-5.4 (Stat 477) Claim Severity Models Brian Hartman - BYU 1 / 1 Introduction Introduction Given that a claim occurs, the (individual) claim size X is typically referred to as claim severity. While typically this may be of continuous random variables, sometimes claim sizes can be considered discrete. When modeling claims severity, insurers are usually concerned with the tails of the distribution. There are certain types of insurance contracts with what are called long tails. Sections 5.3-5.4 (Stat 477) Claim Severity Models Brian Hartman - BYU 2 / 1 Introduction parametric class Parametric distributions A parametric distribution consists of a set of distribution functions with each member determined by specifying one or more values called \parameters". The parameter is fixed and finite, and it could be a one value or several in which case we call it a vector of parameters. Parameter vector could be denoted by θ. The Normal distribution is a clear example: 1 −(x−µ)2=2σ2 fX (x) = p e ; 2πσ where the parameter vector θ = (µ, σ). It is well known that µ is the mean and σ2 is the variance. Some important properties: Standard Normal when µ = 0 and σ = 1. X−µ If X ∼ N(µ, σ), then Z = σ ∼ N(0; 1). Sums of Normal random variables is again Normal. If X ∼ N(µ, σ), then cX ∼ N(cµ, cσ). Sections 5.3-5.4 (Stat 477) Claim Severity Models Brian Hartman - BYU 3 / 1 Introduction some claim size distributions Some parametric claim size distributions Normal - easy to work with, but careful with getting negative claims. -
Package 'Distributional'
Package ‘distributional’ February 2, 2021 Title Vectorised Probability Distributions Version 0.2.2 Description Vectorised distribution objects with tools for manipulating, visualising, and using probability distributions. Designed to allow model prediction outputs to return distributions rather than their parameters, allowing users to directly interact with predictive distributions in a data-oriented workflow. In addition to providing generic replacements for p/d/q/r functions, other useful statistics can be computed including means, variances, intervals, and highest density regions. License GPL-3 Imports vctrs (>= 0.3.0), rlang (>= 0.4.5), generics, ellipsis, stats, numDeriv, ggplot2, scales, farver, digest, utils, lifecycle Suggests testthat (>= 2.1.0), covr, mvtnorm, actuar, ggdist RdMacros lifecycle URL https://pkg.mitchelloharawild.com/distributional/, https: //github.com/mitchelloharawild/distributional BugReports https://github.com/mitchelloharawild/distributional/issues Encoding UTF-8 Language en-GB LazyData true Roxygen list(markdown = TRUE, roclets=c('rd', 'collate', 'namespace')) RoxygenNote 7.1.1 1 2 R topics documented: R topics documented: autoplot.distribution . .3 cdf..............................................4 density.distribution . .4 dist_bernoulli . .5 dist_beta . .6 dist_binomial . .7 dist_burr . .8 dist_cauchy . .9 dist_chisq . 10 dist_degenerate . 11 dist_exponential . 12 dist_f . 13 dist_gamma . 14 dist_geometric . 16 dist_gumbel . 17 dist_hypergeometric . 18 dist_inflated . 20 dist_inverse_exponential . 20 dist_inverse_gamma -
Iam 530 Elements of Probability and Statistics
IAM 530 ELEMENTS OF PROBABILITY AND STATISTICS LECTURE 4-SOME DISCERETE AND CONTINUOUS DISTRIBUTION FUNCTIONS SOME DISCRETE PROBABILITY DISTRIBUTIONS Degenerate, Uniform, Bernoulli, Binomial, Poisson, Negative Binomial, Geometric, Hypergeometric DEGENERATE DISTRIBUTION • An rv X is degenerate at point k if 1, Xk P X x 0, ow. The cdf: 0, Xk F x P X x 1, Xk UNIFORM DISTRIBUTION • A finite number of equally spaced values are equally likely to be observed. 1 P(X x) ; x 1,2,..., N; N 1,2,... N • Example: throw a fair die. P(X=1)=…=P(X=6)=1/6 N 1 (N 1)(N 1) E(X) ; Var(X) 2 12 BERNOULLI DISTRIBUTION • An experiment consists of one trial. It can result in one of 2 outcomes: Success or Failure (or a characteristic being Present or Absent). • Probability of Success is p (0<p<1) 1 with probability p Xp;0 1 0 with probability 1 p P(X x) px (1 p)1 x for x 0,1; and 0 p 1 1 E(X ) xp(y) 0(1 p) 1p p y 0 E X 2 02 (1 p) 12 p p V (X ) E X 2 E(X ) 2 p p2 p(1 p) p(1 p) Binomial Experiment • Experiment consists of a series of n identical trials • Each trial can end in one of 2 outcomes: Success or Failure • Trials are independent (outcome of one has no bearing on outcomes of others) • Probability of Success, p, is constant for all trials • Random Variable X, is the number of Successes in the n trials is said to follow Binomial Distribution with parameters n and p • X can take on the values x=0,1,…,n • Notation: X~Bin(n,p) Consider outcomes of an experiment with 3 Trials : SSS y 3 P(SSS) P(Y 3) p(3) p3 SSF, SFS, FSS y 2 P(SSF SFS FSS) P(Y 2) p(2) 3p2 (1 p) SFF, FSF, FFS y 1 P(SFF FSF FFS ) P(Y 1) p(1) 3p(1 p)2 FFF y 0 P(FFF ) P(Y 0) p(0) (1 p)3 In General: n n! 1) # of ways of arranging x S s (and (n x) F s ) in a sequence of n positions x x!(n x)! 2) Probability of each arrangement of x S s (and (n x) F s ) p x (1 p)n x n 3)P(X x) p(x) p x (1 p)n x x 0,1,..., n x • Example: • There are black and white balls in a box. -
The Length-Biased Versus Random Sampling for the Binomial and Poisson Events Makarand V
Journal of Modern Applied Statistical Methods Volume 12 | Issue 1 Article 10 5-1-2013 The Length-Biased Versus Random Sampling for the Binomial and Poisson Events Makarand V. Ratnaparkhi Wright State University, [email protected] Uttara V. Naik-Nimbalkar Pune University, Pune, India Follow this and additional works at: http://digitalcommons.wayne.edu/jmasm Part of the Applied Statistics Commons, Social and Behavioral Sciences Commons, and the Statistical Theory Commons Recommended Citation Ratnaparkhi, Makarand V. and Naik-Nimbalkar, Uttara V. (2013) "The Length-Biased Versus Random Sampling for the Binomial and Poisson Events," Journal of Modern Applied Statistical Methods: Vol. 12 : Iss. 1 , Article 10. DOI: 10.22237/jmasm/1367381340 Available at: http://digitalcommons.wayne.edu/jmasm/vol12/iss1/10 This Regular Article is brought to you for free and open access by the Open Access Journals at DigitalCommons@WayneState. It has been accepted for inclusion in Journal of Modern Applied Statistical Methods by an authorized editor of DigitalCommons@WayneState. Journal of Modern Applied Statistical Methods Copyright © 2013 JMASM, Inc. May 2013, Vol. 12, No. 1, 54-57 1538 – 9472/13/$95.00 The Length-Biased Versus Random Sampling for the Binomial and Poisson Events Makarand V. Ratnaparkhi Uttara V. Naik-Nimbalkar Wright State University, Pune University, Dayton, OH Pune, India The equivalence between the length-biased and the random sampling on a non-negative, discrete random variable is established. The length-biased versions of the binomial and Poisson distributions are discussed. Key words: Length-biased data, weighted distributions, binomial, Poisson, convolutions. Introduction binomial distribution (probabilities), which was The occurrence of so-called length-biased data appropriate at that time. -
1 Stable Distributions in Streaming Computations
1 Stable Distributions in Streaming Computations Graham Cormode1 and Piotr Indyk2 1 AT&T Labs – Research, 180 Park Avenue, Florham Park NJ, [email protected] 2 Laboratory for Computer Science, Massachusetts Institute of Technology, Cambridge MA, [email protected] 1.1 Introduction In many streaming scenarios, we need to measure and quantify the data that is seen. For example, we may want to measure the number of distinct IP ad- dresses seen over the course of a day, compute the difference between incoming and outgoing transactions in a database system or measure the overall activity in a sensor network. More generally, we may want to cluster readings taken over periods of time or in different places to find patterns, or find the most similar signal from those previously observed to a new observation. For these measurements and comparisons to be meaningful, they must be well-defined. Here, we will use the well-known and widely used Lp norms. These encom- pass the familiar Euclidean (root of sum of squares) and Manhattan (sum of absolute values) norms. In the examples mentioned above—IP traffic, database relations and so on—the data can be modeled as a vector. For example, a vector representing IP traffic grouped by destination address can be thought of as a vector of length 232, where the ith entry in the vector corresponds to the amount of traffic to address i. For traffic between (source, destination) pairs, then a vec- tor of length 264 is defined. The number of distinct addresses seen in a stream corresponds to the number of non-zero entries in a vector of counts; the differ- ence in traffic between two time-periods, grouped by address, corresponds to an appropriate computation on the vector formed by subtracting two vectors, and so on. -
Bivariate Burr Distributions by Extending the Defining Equation
DECLARATION This thesis contains no material which has been accepted for the award of any other degree or diploma in any university and to the best ofmy knowledge and belief, it contains no material previously published by any other person, except where due references are made in the text ofthe thesis !~ ~ Cochin-22 BISMI.G.NADH June 2005 ACKNOWLEDGEMENTS I wish to express my profound gratitude to Dr. V.K. Ramachandran Nair, Professor, Department of Statistics, CUSAT for his guidance, encouragement and support through out the development ofthis thesis. I am deeply indebted to Dr. N. Unnikrishnan Nair, Fonner Vice Chancellor, CUSAT for the motivation, persistent encouragement and constructive criticism through out the development and writing of this thesis. The co-operation rendered by all teachers in the Department of Statistics, CUSAT is also thankfully acknowledged. I also wish to express great happiness at the steadfast encouragement rendered by my family. Finally I dedicate this thesis to the loving memory of my father Late. Sri. C.K. Gopinath. BISMI.G.NADH CONTENTS Page CHAPTER I INTRODUCTION 1 1.1 Families ofDistributions 1.2· Burr system 2 1.3 Present study 17 CHAPTER II BIVARIATE BURR SYSTEM OF DISTRIBUTIONS 18 2.1 Introduction 18 2.2 Bivariate Burr system 21 2.3 General Properties of Bivariate Burr system 23 2.4 Members ofbivariate Burr system 27 CHAPTER III CHARACTERIZATIONS OF BIVARIATE BURR 33 SYSTEM 3.1 Introduction 33 3.2 Characterizations ofbivariate Burr system using reliability 33 concepts 3.3 Characterization ofbivariate -
The Multivariate Normal Distribution=1See Last Slide For
Moment-generating Functions Definition Properties χ2 and t distributions The Multivariate Normal Distribution1 STA 302 Fall 2017 1See last slide for copyright information. 1 / 40 Moment-generating Functions Definition Properties χ2 and t distributions Overview 1 Moment-generating Functions 2 Definition 3 Properties 4 χ2 and t distributions 2 / 40 Moment-generating Functions Definition Properties χ2 and t distributions Joint moment-generating function Of a p-dimensional random vector x t0x Mx(t) = E e x t +x t +x t For example, M (t1; t2; t3) = E e 1 1 2 2 3 3 (x1;x2;x3) Just write M(t) if there is no ambiguity. Section 4.3 of Linear models in statistics has some material on moment-generating functions (optional). 3 / 40 Moment-generating Functions Definition Properties χ2 and t distributions Uniqueness Proof omitted Joint moment-generating functions correspond uniquely to joint probability distributions. M(t) is a function of F (x). Step One: f(x) = @ ··· @ F (x). @x1 @xp @ @ R x2 R x1 For example, f(y1; y2) dy1dy2 @x1 @x2 −∞ −∞ 0 Step Two: M(t) = R ··· R et xf(x) dx Could write M(t) = g (F (x)). Uniqueness says the function g is one-to-one, so that F (x) = g−1 (M(t)). 4 / 40 Moment-generating Functions Definition Properties χ2 and t distributions g−1 (M(t)) = F (x) A two-variable example g−1 (M(t)) = F (x) −1 R 1 R 1 x1t1+x2t2 R x2 R x1 g −∞ −∞ e f(x1; x2) dx1dx2 = −∞ −∞ f(y1; y2) dy1dy2 5 / 40 Moment-generating Functions Definition Properties χ2 and t distributions Theorem Two random vectors x1 and x2 are independent if and only if the moment-generating function of their joint distribution is the product of their moment-generating functions. -
Loss Distributions
Munich Personal RePEc Archive Loss Distributions Burnecki, Krzysztof and Misiorek, Adam and Weron, Rafal 2010 Online at https://mpra.ub.uni-muenchen.de/22163/ MPRA Paper No. 22163, posted 20 Apr 2010 10:14 UTC Loss Distributions1 Krzysztof Burneckia, Adam Misiorekb,c, Rafał Weronb aHugo Steinhaus Center, Wrocław University of Technology, 50-370 Wrocław, Poland bInstitute of Organization and Management, Wrocław University of Technology, 50-370 Wrocław, Poland cSantander Consumer Bank S.A., Wrocław, Poland Abstract This paper is intended as a guide to statistical inference for loss distributions. There are three basic approaches to deriving the loss distribution in an insurance risk model: empirical, analytical, and moment based. The empirical method is based on a sufficiently smooth and accurate estimate of the cumulative distribution function (cdf) and can be used only when large data sets are available. The analytical approach is probably the most often used in practice and certainly the most frequently adopted in the actuarial literature. It reduces to finding a suitable analytical expression which fits the observed data well and which is easy to handle. In some applications the exact shape of the loss distribution is not required. We may then use the moment based approach, which consists of estimating only the lowest characteristics (moments) of the distribution, like the mean and variance. Having a large collection of distributions to choose from, we need to narrow our selection to a single model and a unique parameter estimate. The type of the objective loss distribution can be easily selected by comparing the shapes of the empirical and theoretical mean excess functions. -
Mixed-Stable Models: an Application to High-Frequency Financial Data
entropy Article Mixed-Stable Models: An Application to High-Frequency Financial Data Igoris Belovas 1,* , Leonidas Sakalauskas 2, Vadimas Starikoviˇcius 3 and Edward W. Sun 4 1 Institute of Data Science and Digital Technologies, Faculty of Mathematics and Informatics, Vilnius University, LT-04812 Vilnius, Lithuania 2 Department of Information Technologies, Faculty of Fundamental Sciences, Vilnius Gediminas Technical University, LT-2040 Vilnius, Lithuania; [email protected] 3 Department of Mathematical Modelling, Faculty of Fundamental Sciences, Vilnius Gediminas Technical University, LT-2040 Vilnius, Lithuania; [email protected] 4 KEDGE Business School, Accounting, Finance, & Economics Department (CFE), Campus Bordeaux, 33405 Talence, France; [email protected] * Correspondence: [email protected] Abstract: The paper extends the study of applying the mixed-stable models to the analysis of large sets of high-frequency financial data. The empirical data under review are the German DAX stock index yearly log-returns series. Mixed-stable models for 29 DAX companies are constructed employing efficient parallel algorithms for the processing of long-term data series. The adequacy of the modeling is verified with the empirical characteristic function goodness-of-fit test. We propose the smart-D method for the calculation of the a-stable probability density function. We study the impact of the accuracy of the computation of the probability density function and the accuracy of ML-optimization on the results of the modeling and processing time. The obtained mixed-stable parameter estimates can be used for the construction of the optimal asset portfolio. Citation: Belovas, I.; Sakalauskas, L.; Starikoviˇcius,V.; Sun, E.W. Keywords: mixed-stable models; high-frequency data; stock index returns Mixed-Stable Models: An Application to High-Frequency Financial Data.