Advances in Deriving the Exact Distribution of Maximum Annual Daily Precipitation
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A Tail Quantile Approximation Formula for the Student T and the Symmetric Generalized Hyperbolic Distribution
A Service of Leibniz-Informationszentrum econstor Wirtschaft Leibniz Information Centre Make Your Publications Visible. zbw for Economics Schlüter, Stephan; Fischer, Matthias J. Working Paper A tail quantile approximation formula for the student t and the symmetric generalized hyperbolic distribution IWQW Discussion Papers, No. 05/2009 Provided in Cooperation with: Friedrich-Alexander University Erlangen-Nuremberg, Institute for Economics Suggested Citation: Schlüter, Stephan; Fischer, Matthias J. (2009) : A tail quantile approximation formula for the student t and the symmetric generalized hyperbolic distribution, IWQW Discussion Papers, No. 05/2009, Friedrich-Alexander-Universität Erlangen-Nürnberg, Institut für Wirtschaftspolitik und Quantitative Wirtschaftsforschung (IWQW), Nürnberg This Version is available at: http://hdl.handle.net/10419/29554 Standard-Nutzungsbedingungen: Terms of use: Die Dokumente auf EconStor dürfen zu eigenen wissenschaftlichen Documents in EconStor may be saved and copied for your Zwecken und zum Privatgebrauch gespeichert und kopiert werden. personal and scholarly purposes. Sie dürfen die Dokumente nicht für öffentliche oder kommerzielle You are not to copy documents for public or commercial Zwecke vervielfältigen, öffentlich ausstellen, öffentlich zugänglich purposes, to exhibit the documents publicly, to make them machen, vertreiben oder anderweitig nutzen. publicly available on the internet, or to distribute or otherwise use the documents in public. Sofern die Verfasser die Dokumente unter Open-Content-Lizenzen (insbesondere CC-Lizenzen) zur Verfügung gestellt haben sollten, If the documents have been made available under an Open gelten abweichend von diesen Nutzungsbedingungen die in der dort Content Licence (especially Creative Commons Licences), you genannten Lizenz gewährten Nutzungsrechte. may exercise further usage rights as specified in the indicated licence. www.econstor.eu IWQW Institut für Wirtschaftspolitik und Quantitative Wirtschaftsforschung Diskussionspapier Discussion Papers No. -
Extreme Value Theory and Backtest Overfitting in Finance
View metadata, citation and similar papers at core.ac.uk brought to you by CORE provided by Bowdoin College Bowdoin College Bowdoin Digital Commons Honors Projects Student Scholarship and Creative Work 2015 Extreme Value Theory and Backtest Overfitting in Finance Daniel C. Byrnes [email protected] Follow this and additional works at: https://digitalcommons.bowdoin.edu/honorsprojects Part of the Statistics and Probability Commons Recommended Citation Byrnes, Daniel C., "Extreme Value Theory and Backtest Overfitting in Finance" (2015). Honors Projects. 24. https://digitalcommons.bowdoin.edu/honorsprojects/24 This Open Access Thesis is brought to you for free and open access by the Student Scholarship and Creative Work at Bowdoin Digital Commons. It has been accepted for inclusion in Honors Projects by an authorized administrator of Bowdoin Digital Commons. For more information, please contact [email protected]. Extreme Value Theory and Backtest Overfitting in Finance An Honors Paper Presented for the Department of Mathematics By Daniel Byrnes Bowdoin College, 2015 ©2015 Daniel Byrnes Acknowledgements I would like to thank professor Thomas Pietraho for his help in the creation of this thesis. The revisions and suggestions made by several members of the math faculty were also greatly appreciated. I would also like to thank the entire department for their support throughout my time at Bowdoin. 1 Contents 1 Abstract 3 2 Introduction4 3 Background7 3.1 The Sharpe Ratio.................................7 3.2 Other Performance Measures.......................... 10 3.3 Example of an Overfit Strategy......................... 11 4 Modes of Convergence for Random Variables 13 4.1 Random Variables and Distributions...................... 13 4.2 Convergence in Distribution.......................... -
Algorithms for Operations on Probability Distributions in a Computer Algebra System
W&M ScholarWorks Dissertations, Theses, and Masters Projects Theses, Dissertations, & Master Projects 2001 Algorithms for operations on probability distributions in a computer algebra system Diane Lynn Evans College of William & Mary - Arts & Sciences Follow this and additional works at: https://scholarworks.wm.edu/etd Part of the Mathematics Commons, and the Statistics and Probability Commons Recommended Citation Evans, Diane Lynn, "Algorithms for operations on probability distributions in a computer algebra system" (2001). Dissertations, Theses, and Masters Projects. Paper 1539623382. https://dx.doi.org/doi:10.21220/s2-bath-8582 This Dissertation is brought to you for free and open access by the Theses, Dissertations, & Master Projects at W&M ScholarWorks. It has been accepted for inclusion in Dissertations, Theses, and Masters Projects by an authorized administrator of W&M ScholarWorks. For more information, please contact [email protected]. Reproduced with with permission permission of the of copyright the copyright owner. owner.Further reproductionFurther reproduction prohibited without prohibited permission. without permission. ALGORITHMS FOR OPERATIONS ON PROBABILITY DISTRIBUTIONS IN A COMPUTER ALGEBRA SYSTEM A Dissertation Presented to The Faculty of the Department of Applied Science The College of William & Mary in Virginia In Partial Fulfillment Of the Requirements for the Degree of Doctor of Philosophy by Diane Lynn Evans July 2001 Reproduced with permission of the copyright owner. Further reproduction prohibited without permission. UMI Number: 3026405 Copyright 2001 by Evans, Diane Lynn All rights reserved. ___ ® UMI UMI Microform 3026405 Copyright 2001 by Bell & Howell Information and Learning Company. All rights reserved. This microform edition is protected against unauthorized copying under Title 17, United States Code. -
Generating Random Samples from User-Defined Distributions
The Stata Journal (2011) 11, Number 2, pp. 299–304 Generating random samples from user-defined distributions Katar´ına Luk´acsy Central European University Budapest, Hungary lukacsy [email protected] Abstract. Generating random samples in Stata is very straightforward if the distribution drawn from is uniform or normal. With any other distribution, an inverse method can be used; but even in this case, the user is limited to the built- in functions. For any other distribution functions, their inverse must be derived analytically or numerical methods must be used if analytical derivation of the inverse function is tedious or impossible. In this article, I introduce a command that generates a random sample from any user-specified distribution function using numeric methods that make this command very generic. Keywords: st0229, rsample, random sample, user-defined distribution function, inverse method, Monte Carlo exercise 1 Introduction In statistics, a probability distribution identifies the probability of a random variable. If the random variable is discrete, it identifies the probability of each value of this vari- able. If the random variable is continuous, it defines the probability that this variable’s value falls within a particular interval. The probability distribution describes the range of possible values that a random variable can attain, further referred to as the sup- port interval, and the probability that the value of the random variable is within any (measurable) subset of that range. Random sampling refers to taking a number of independent observations from a probability distribution. Typically, the parameters of the probability distribution (of- ten referred to as true parameters) are unknown, and the aim is to retrieve them using various estimation methods on the random sample generated from this probability dis- tribution. -
Random Variables Generation
Random Variables Generation Revised version of the slides based on the book Discrete-Event Simulation: a first course L.L. Leemis & S.K. Park Section(s) 6.1, 6.2, 7.1, 7.2 c 2006 Pearson Ed., Inc. 0-13-142917-5 Discrete-Event Simulation Random Variables Generation 1/80 Introduction Monte Carlo Simulators differ from Trace Driven simulators because of the use of Random Number Generators to represent the variability that affects the behaviors of real systems. Uniformly distributed random variables are the most elementary representations that we can use in Monte Carlo simulation, but are not enough to capture the complexity of real systems. We must thus devise methods for generating instances (variates) of arbitrary random variables Properly using uniform random numbers, it is possible to obtain this result. In the sequel we will first recall some basic properties of Discrete and Continuous random variables and then we will discuss several methods to obtain their variates Discrete-Event Simulation Random Variables Generation 2/80 Basic Probability Concepts Empirical Probability, derives from performing an experiment many times n and counting the number of occurrences na of an event A The relative frequency of occurrence of event is na/n The frequency theory of probability asserts thatA the relative frequency converges as n → ∞ n Pr( )= lim a A n→∞ n Axiomatic Probability is a formal, set-theoretic approach Mathematically construct the sample space and calculate the number of events A The two are complementary! Discrete-Event Simulation Random -
On Half-Cauchy Distribution and Process
International Journal of Statistika and Mathematika, ISSN: 2277- 2790 E-ISSN: 2249-8605, Volume 3, Issue 2, 2012 pp 77-81 On Half-Cauchy Distribution and Process Elsamma Jacob1 , K Jayakumar2 1Malabar Christian College, Calicut, Kerala, INDIA. 2Department of Statistics, University of Calicut, Kerala, INDIA. Corresponding addresses: [email protected], [email protected] Research Article Abstract: A new form of half- Cauchy distribution using sin ξ cos ξ Marshall-Olkin transformation is introduced. The properties of () = − ξ, () = ξ, ≥ 0 the new distribution such as density, cumulative distribution ξ ξ function, quantiles, measure of skewness and distribution of the extremes are obtained. Time series models with half-Cauchy Remark 1.1. For the HC distribution the moments do distribution as stationary marginal distributions are not not exist. developed so far. We develop first order autoregressive process Remark 1.2. The HC distribution is infinitely divisible with the new distribution as stationary marginal distribution and (Bondesson (1987)) and self decomposable (Diedhiou the properties of the process are studied. Application of the (1998)). distribution in various fields is also discussed. Keywords: Autoregressive Process, Geometric Extreme Stable, Relationship with other distributions: Half-Cauchy Distribution, Skewness, Stationarity, Quantiles. 1. Let Y be a folded t variable with pdf given by 1. Introduction: ( ) > 0, (1.5) The half Cauchy (HC) distribution is derived from 2Γ( ) () = 1 + , ν ∈ , the standard Cauchy distribution by folding the ν ()√νπ curve on the origin so that only positive values can be observed. A continuous random variable X is said When ν = 1 , (1.5) reduces to 2 1 > 0 to have the half Cauchy distribution if its survival () = , function is given by 1 + (x)=1 − tan , > 0 (1.1) Thus, HC distribution coincides with the folded t distribution with = 1 degree of freedom. -
Parametric (Theoretical) Probability Distributions. (Wilks, Ch. 4) Discrete
6 Parametric (theoretical) probability distributions. (Wilks, Ch. 4) Note: parametric: assume a theoretical distribution (e.g., Gauss) Non-parametric: no assumption made about the distribution Advantages of assuming a parametric probability distribution: Compaction: just a few parameters Smoothing, interpolation, extrapolation x x + s Parameter: e.g.: µ,σ population mean and standard deviation Statistic: estimation of parameter from sample: x,s sample mean and standard deviation Discrete distributions: (e.g., yes/no; above normal, normal, below normal) Binomial: E = 1(yes or success); E = 0 (no, fail). These are MECE. 1 2 P(E ) = p P(E ) = 1− p . Assume N independent trials. 1 2 How many “yes” we can obtain in N independent trials? x = (0,1,...N − 1, N ) , N+1 possibilities. Note that x is like a dummy variable. ⎛ N ⎞ x N − x ⎛ N ⎞ N ! P( X = x) = p 1− p , remember that = , 0!= 1 ⎜ x ⎟ ( ) ⎜ x ⎟ x!(N x)! ⎝ ⎠ ⎝ ⎠ − Bernouilli is the binomial distribution with a single trial, N=1: x = (0,1), P( X = 0) = 1− p, P( X = 1) = p Geometric: Number of trials until next success: i.e., x-1 fails followed by a success. x−1 P( X = x) = (1− p) p x = 1,2,... 7 Poisson: Approximation of binomial for small p and large N. Events occur randomly at a constant rate (per N trials) µ = Np . The rate per trial p is low so that events in the same period (N trials) are approximately independent. Example: assume the probability of a tornado in a certain county on a given day is p=1/100. -
Handbook on Probability Distributions
R powered R-forge project Handbook on probability distributions R-forge distributions Core Team University Year 2009-2010 LATEXpowered Mac OS' TeXShop edited Contents Introduction 4 I Discrete distributions 6 1 Classic discrete distribution 7 2 Not so-common discrete distribution 27 II Continuous distributions 34 3 Finite support distribution 35 4 The Gaussian family 47 5 Exponential distribution and its extensions 56 6 Chi-squared's ditribution and related extensions 75 7 Student and related distributions 84 8 Pareto family 88 9 Logistic distribution and related extensions 108 10 Extrem Value Theory distributions 111 3 4 CONTENTS III Multivariate and generalized distributions 116 11 Generalization of common distributions 117 12 Multivariate distributions 133 13 Misc 135 Conclusion 137 Bibliography 137 A Mathematical tools 141 Introduction This guide is intended to provide a quite exhaustive (at least as I can) view on probability distri- butions. It is constructed in chapters of distribution family with a section for each distribution. Each section focuses on the tryptic: definition - estimation - application. Ultimate bibles for probability distributions are Wimmer & Altmann (1999) which lists 750 univariate discrete distributions and Johnson et al. (1994) which details continuous distributions. In the appendix, we recall the basics of probability distributions as well as \common" mathe- matical functions, cf. section A.2. And for all distribution, we use the following notations • X a random variable following a given distribution, • x a realization of this random variable, • f the density function (if it exists), • F the (cumulative) distribution function, • P (X = k) the mass probability function in k, • M the moment generating function (if it exists), • G the probability generating function (if it exists), • φ the characteristic function (if it exists), Finally all graphics are done the open source statistical software R and its numerous packages available on the Comprehensive R Archive Network (CRAN∗). -
5 Introduction to the Theory of Order Statistics and Rank Statistics • This
5 Introduction to the Theory of Order Statistics and Rank Statistics • This section will contain a summary of important definitions and theorems that will be useful for understanding the theory of order and rank statistics. In particular, results will be presented for linear rank statistics. • Many nonparametric tests are based on test statistics that are linear rank statistics. { For one sample: The Wilcoxon-Signed Rank Test is based on a linear rank statistic. { For two samples: The Mann-Whitney-Wilcoxon Test, the Median Test, the Ansari- Bradley Test, and the Siegel-Tukey Test are based on linear rank statistics. • Most of the information in this section can be found in Randles and Wolfe (1979). 5.1 Order Statistics • Let X1;X2;:::;Xn be a random sample of continuous random variables having cdf F (x) and pdf f(x). th • Let X(i) be the i smallest random variable (i = 1; 2; : : : ; n). • X(1);X(2);:::;X(n) are referred to as the order statistics for X1;X2;:::;Xn. By defini- tion, X(1) < X(2) < ··· < X(n). Theorem 5.1: Let X(1) < X(2) < ··· < X(n) be the order statistics for a random sample from a distribution with cdf F (x) and pdf f(x). The joint density for the order statistics is n Y g(x(1); x(2); : : : ; x(n)) = n! f(x(i)) for − 1 < x(1) < x(2) < ··· < x(n) < 1 (16) i=1 = 0 otherwise th Theorem 5.2: The marginal density for the j order statistic X(j) (j = 1; 2; : : : ; n) is n! g (t) = [F (t)]j−1 [1 − F (t)]n−j f(t) − 1 < t < 1: j (j − 1)!(n − j)! • For random variable X with cdf F (x), the inverse distribution F −1(·) is defined as F −1(y) = inffx : F (x) ≥ yg 0 < y < 1: • If F (x) is strictly increasing between 0 and 1, then there is only one x such that F (x) = y. -
Multivariate Non-Normally Distributed Random Variables in Climate Research – Introduction to the Copula Approach Christian Schoelzel, P
Multivariate non-normally distributed random variables in climate research – introduction to the copula approach Christian Schoelzel, P. Friederichs To cite this version: Christian Schoelzel, P. Friederichs. Multivariate non-normally distributed random variables in cli- mate research – introduction to the copula approach. Nonlinear Processes in Geophysics, European Geosciences Union (EGU), 2008, 15 (5), pp.761-772. cea-00440431 HAL Id: cea-00440431 https://hal-cea.archives-ouvertes.fr/cea-00440431 Submitted on 10 Dec 2009 HAL is a multi-disciplinary open access L’archive ouverte pluridisciplinaire HAL, est archive for the deposit and dissemination of sci- destinée au dépôt et à la diffusion de documents entific research documents, whether they are pub- scientifiques de niveau recherche, publiés ou non, lished or not. The documents may come from émanant des établissements d’enseignement et de teaching and research institutions in France or recherche français ou étrangers, des laboratoires abroad, or from public or private research centers. publics ou privés. Nonlin. Processes Geophys., 15, 761–772, 2008 www.nonlin-processes-geophys.net/15/761/2008/ Nonlinear Processes © Author(s) 2008. This work is licensed in Geophysics under a Creative Commons License. Multivariate non-normally distributed random variables in climate research – introduction to the copula approach C. Scholzel¨ 1,2 and P. Friederichs2 1Laboratoire des Sciences du Climat et l’Environnement (LSCE), Gif-sur-Yvette, France 2Meteorological Institute at the University of Bonn, Germany Received: 28 November 2007 – Revised: 28 August 2008 – Accepted: 28 August 2008 – Published: 21 October 2008 Abstract. Probability distributions of multivariate random nature can be found in e.g. Lorenz (1964); Eckmann and Ru- variables are generally more complex compared to their uni- elle (1985). -
Introduction to Monte Carlo Simulations Ebrahim Shayesteh Agenda
F19: Introduction to Monte Carlo simulations Ebrahim Shayesteh Agenda . Introduction and repetition . Monte Carlo methods: Background, Introduction, Motivation . Example 1: Buffon’s needle . Simple Sampling . Example 2: Travel time from A to B . Accuracy: Variance reduction techniques . VRT 1: Complementary random numbers . Example 3: DC OPF problem 2 Repetition: fault models . Note: "Non-repairable systems” . A summary of functions to describe the stochastic variable T (when a failure occurs): . Cumulative distribution function: F t PT t . survivor Rt P T t 1 F t function: . Probability f (t) F t R t density function: f t F t . Failure rate: zt Rt 1 F t 3 Repetition: repairable systems . Repairable systems: ”alternating renewal process” X(t) 1 0 t T 1 D 1 T 2 D 2 T 3 D 3 T 4 . Mean Time To Failure (MTTF) . Mean Down Time (MDT) . Mean Time To Repair (MTTR), sometimes, but not always the same as MDT . Mean Time Between Failure (MTBF = MTTF + MDT) 4 Repetition: repairable systems . The “availability” for a unit is defined as the probability that the unit is operational at a given time t 1 . Note: – if the unit cannot be repaired A(t)=R(t) – if the unit can be repaired, the availability will depend both on the lifetime distribution and the repair time. 5 Repetition: repairable systems . The share of when the unit has been working thus becomes: n 1 n T T i n i i 1 i 1 n n 11n n TDi i Ti D i i 11i n i 11n i . It results when ∞ in: ET MTTF Aav ET ED MTTF MDT 6 Repetition: repairable systems . -
Maxima of Independent, Non-Identically Distributed
Bernoulli 21(1), 2015, 38–61 DOI: 10.3150/13-BEJ560 Maxima of independent, non-identically distributed Gaussian vectors SEBASTIAN ENGELKE1,2, ZAKHAR KABLUCHKO3 and MARTIN SCHLATHER4 1Institut f¨ur Mathematische Stochastik, Georg-August-Universit¨at G¨ottingen, Goldschmidtstr. 7, D-37077 G¨ottingen, Germany. E-mail: [email protected] 2Facult´edes Hautes Etudes Commerciales, Universit´ede Lausanne, Extranef, UNIL-Dorigny, CH-1015 Lausanne, Switzerland 3Institut f¨ur Stochastik, Universit¨at Ulm, Helmholtzstr. 18, D-89069 Ulm, Germany. E-mail: [email protected] 4Institut f¨ur Mathematik, Universit¨at Mannheim, A5, 6, D-68131 Mannheim, Germany. E-mail: [email protected] d Let Xi,n, n ∈ N, 1 ≤ i ≤ n, be a triangular array of independent R -valued Gaussian random vectors with correlation matrices Σi,n. We give necessary conditions under which the row-wise maxima converge to some max-stable distribution which generalizes the class of H¨usler–Reiss distributions. In the bivariate case, the conditions will also be sufficient. Using these results, new models for bivariate extremes are derived explicitly. Moreover, we define a new class of stationary, max-stable processes as max-mixtures of Brown–Resnick processes. As an application, we show that these processes realize a large set of extremal correlation functions, a natural dependence measure for max-stable processes. This set includes all functions ψ(pγ(h)), h ∈ Rd, where ψ is a completely monotone function and γ is an arbitrary variogram. Keywords: extremal correlation function; Gaussian random vectors; H¨usler–Reiss distributions; max-limit theorems; max-stable distributions; triangular arrays 1.