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  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GDiscovering Influential Variables: A Method of Partitions and Genetic Applications
    ¥DÁ¿¤H¡Gù¤pµØ±Ð±Â(­ô­Û¤ñ¨È¤j¾Ç²Î­p¨t)
    ®É¡@¶¡¡G97¦~7¤ë16¤é(¬P´Á¤T)¤W¤È11:00-12:00
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    A trend in all scientific disciplines, based on advances in technology, is the increasing availability of high dimensional data in which are buried important information. A current urgent challenge to statisticians is to develop effective methods of finding the useful information from the vast amounts of messy and noisy data available, most of which are noninformative.
    We introduce a general computer intensive approach, based on a method proposed by Lo and Zheng for detecting which, of many potential explanatory variables, have an influence on a dependent variable Y. This approach is suited to detect influential variables, where causal effects depend on the confluence of values with other variables. It has the advantage of avoiding a difficult direct analysis involving possibly thousands of variables, by dealing with many randomly selected small subsets.
    The main objective is to discover the influential variables, rather than to measure their effects. Once they are detected, the problem of dealing with a much smaller group of influential variables should be vulnerable to appropriate analysis. In a sense, we are confining our attention to locating a few needles in a haystack.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GFrom Glutathione S-Transferase Omega-1 (GSTO1) and -2 (GSTO2) for age-at-onset of Alzheimer disease to a Novel Family-based Association Method
    ¥DÁ¿¤H¡G§õ©É¦p±Ð±Â(Duke University Medical Center)
    ®É¡@¶¡¡G97¦~6¤ë18¤é(¬P´Á¤T)¤U¤È13:00-13:50
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    We previously reported genetic linkage of loci controlling age-at-onset in Alzheimer disease (AD) to a 15 cM region on chromosome 10q.? Given the large number of genes in this initial starting region, we applied our process of ¡§genomic convergence¡¨ to prioritize and reduce the number of candidate genes for further analysis.? As our second convergence factor we performed gene expression studies on hippocampus obtained from AD patients and controls.? Analysis revealed that four of the genes (Stearoyl-CoA desaturase ; NADH-ubiquinone oxidoreductase 1 beta complex 8 ; protease, serine 11; and glutathione S-transferase, omega-1 (GSTO1)) were significantly different in their expression between AD and controls, and mapped to the 10q age-at-onset linkage region, the first convergence factor.? Using 2814 samples from our AD dataset (1773 AD patients), allelic association studies for age-at-onset effects in AD revealed no association for three of the candidates, but a significant association was found for GSTO1 (P=0.007) and a second transcribed member of the GST omega class, GSTO2 (P=0.005), located next to GSTO1.? However, the family-based association methods used in this study focus on quantitative traits only. Since age-at-onset data are censored among unaffected individuals, we subsequently developed a Genetic Association Tests based On Ranks (GATOR) program to analyzed familial quantitative data with and without censoring. The GATOR method was found to have increasing? power in comparison to existing methods (e.g. the QTDT program) when censor rate increases. In addition, GATOR performed better than the logrank and Wilcoxon methods implemented in FBAT program under certain scenario. We applied the GATOR program to GSTO1 and GSTO2, and both genes remain highly significant. As GSTO1 may be involved in the post-translational modification of the inflammatory cytokine Interleukin-1£], these two candidate genes may play an important role in regulating age-at-onset of AD.

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  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GAnalysis of longitudinal trinomial outcome data
    ¥DÁ¿¤H¡G¸â¤åÄ£±Ð±Â(¬ü°ê¼w¦{¤j¾Ç¤½¦@½Ã¥Í¾Ç°|¥Íª«²Î­p¨t)
    ®É¡@¶¡¡G97¦~5¤ë15¤é(¬P´Á¥|)¤U¤È14:30-15:20
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Analysis of categorical outcomes in a longitudinal study has been an important statistical issue. Continuous outcome in a similar study design is commonly handled by the mixed effects model. The longitudinal binary or Poisson-like outcome analysis is often handled by the generalized estimation equation (GEE) method. Neither method is appropriate for analyzing a trinomial outcome in a longitudinal study. In addition, methods that rely upon GEE or mixed effects models are unsuitable in instances when the focus of a longitudinal study is on the rate of moving from one category to another. In this research, the relationship between a trinomial longitudinal outcome and independent variables are examined. The primary assumption is that the within-subject changes of the outcome variable follow a continuous-time Markov model. An empirical study was conducted to evaluate the estimators. The technique was then applied to the Project HOME data, a population-based group intervention trial, to identify factors associated with subject changes in stage; from precontemplation to contemplation and from contemplation to action, following the health behavior Transtheoretical model.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GGlobal Testing of Differential Gene Expression in Functional Groups
    ¥DÁ¿¤H¡G½²¬F¦w±Ð±Â(¤¤°êÂåÃĤj¾Ç¥Íª«²Î­p¤¤¤ß)
    ®É¡@¶¡¡G97¦~5¤ë9¤é(¬P´Á¤­)¤W¤È10:40-11:30
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract
    Recent advances in cDNA microarray technology provide exciting tools for studying the expression levels of thousands of distinct genes simultaneously. An important aim in such experiments is to identify a subset of genes that are differentially expressed genes between different conditions. Recently, in addition to attempting to understand biological functions of each individual gene, gene-class testing (GCT) or gene set enrichment analysis (GSEA) has been proposed for gene expression analysis. A gene class may refer to a group of genes with related functions or a set of genes grouped together based on biologically relevant information.

    Tian et al. (2005) presented two hypotheses for the purpose of GSEA, in which the Q1 hypothesis tests the relative strength of association with the phenotypes among the gene classes, and the Q2 hypothesis assesses the statistical significance. These two hypotheses are related but not equivalent. In this talk, I will investigate the null distributions of gene classes under Q1 and Q2 for three one-sided and two two-sided test statistics. We applied the five statistics to a diabetes dataset with 143 gene classes. In each statistic, the null distributions among the 143 gene classes under Q1 are different. In each statistic, the null distributions of the gene classes under Q1 and under Q2 are different, and their rankings of significance can be different too. We clarify the one-sided and two-sided hypotheses, and discuss some issues regarding the Q1 and Q2 hypotheses for gene class ranking in the GCT.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GFrom Microarray Profiling to Biological Data Validation
    ¥DÁ¿¤H¡G¶À©_­^±Ð±Â(°ê¥ß¶§©ú¤j¾ÇÁ{§ÉÂå¾Ç¬ã¨s©Ò)
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    The development of microarrays permits us to monitor transcriptomes on a genome-wide scale. To validate microarray measurements, quantitative-real time-reverse transcription PCR (Q-RT-PCR) is one of the most robust and commonly used approaches. The new challenge in gene quantification analysis is how to explicitly incorporate statistical estimation in such studies. In the realm of statistical analysis, the various available methods of the probe level normalization for microarray analysis may result in distinctly different target selections and variation in the scores for the correlation between microarray and Q-RT-PCR. Moreover, it remains a major challenge to identify a proper internal control for Q-RT-PCR when confirming microarray measurements. Sixty-six Affymetrix microarray slides using lung adenocarcinoma tissue RNAs were analyzed by a statistical re-sampling method in order to detect genes with minimal variation in gene expression. By this approach, we identified DDX5 as a novel internal control for Q-RT-PCR. Twenty-three genes, which were differentially expressed between adjacent normal and tumor samples, were selected and analyzed using 24 paired lung adenocarcinoma samples by Q-RT-PCR using two internal controls, DDX5 and GAPDH. The percentage correlation between Q-RT-PCR and microarray were 70% and 48% by using DDX5 and GAPDH as internal controls, respectively. Together, these quantification strategies for Q-RT-PCR data processing procedure, which focused on minimal variation, ought to significantly facilitate internal control evaluation and selection for Q-RT-PCR when corroborating microarray data.

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  • ¤E¤Q¤C¾Ç¦~«×²Î­p¾Ç¬ã¨s©ÒºÓ¤h¯ZºÂ¸Õ¤f¸Õ®É¶¡ªí (2008/04/18)

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  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GThe Graphical Display of Missing Values: Is Something Missing?
    ¥DÁ¿¤H¡GProf. Antony Unwin (Universitat Augsburg, Germany)
    ®É¡@¶¡¡G97¦~3¤ë21¤é(¬P´Á¤­)¤W¤È10:40-11:30
    (¤W¤È10:20-10:40¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Missing values can influence statistical analyses and it is important not to neglect them. Although there have been considerable improvements in dealing with missing values analytically (especially with the development of multiple imputation methods), many assumptions have to be made. Graphical methods are valuable for identifying patterns of missings, for assessing their effect, and for qualifying conclusions, yet they are do not seem to be used much. Why are these methods missing?  This paper describes ways of incorporating missing values into statistical graphics and illustrates their application.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GOptimal Strategies for Various Casinos
    ¥DÁ¿¤H¡G³¯¤å¾Ë±Ð±Â(Department of Mathematics, University of Miami)
    ®É¡@¶¡¡G96¦~12¤ë28¤é(¬P´Á¤­)¤W¤È10:40-11:30
    (¤W¤È10:20-10:40¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    In this talk, we will discuss optimal strategies for Red-and-Black Casino, Primitive Casino, and Vardi Casino under various conditions. Some interesting open problems will be also mentioned for further research.

    (This is a joint work with Yu-Chung Wei and Shu-Hui Wen)

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GIssues on Computer Search for Large Order Multiple Recursive Generators
    ¥DÁ¿¤H¡G¾H§Q·½±Ð±Â Department of Mathematical Sciences The University of Memphis
    ®É¡@¶¡¡G96¦~12¤ë14¤é(¬P´Á¤­)¤W¤È11:10-12:00
    (¤W¤È10:50-11:10¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Multiple Recursive Generators (MRGs) have become the most popular random number generators recently. They compute the next value iteratively from the previous k values using a k-th order recurrence equation which, in turn, corresponds to a k-th degree primitive polynomial under a prime modulus p. In general, when k and p are large, checking if a k-th degree polynomial is primitive under a prime modulus p is known to be a hard problem. A common approach is to check the conditions given in Alanen and Knuth [1964] and Knuth [1998]. However, as mentioned in Deng [2004], this approach has two obvious problems: (a) it requires the complete factorization of pk-1, which can be difficult; (b) it does not provide any early exit strategy for non-primitive polynomials. To avoid (a), one can consider a prime order k and prime modulus p such that (pk-1)/(p-1) is also a prime number as considered in L'Ecuyer [1999] and Deng [2004]. To avoid (b), one can use a more efficient iterative irreducibility test proposed in Deng [2004]. In this talk, we survey several leading probabilistic and deterministic methods for the problems of primality testing and irreducibility testing. To test primality of a large number, it is known that probabilistic methods are much faster than deterministic methods. On the other hand, a probabilistic algorithm in fact has a very tiny probability of, say, 10-200 to commit a false positive error in the test result. Moreover, even when such an unlikely event had happened, for a specific choice of k and p, it can be argued that such an error has a negligible effect on the successful search of a primitive polynomial. We perform a computer search for large-order DX generators proposed in Deng and Xu [2003] and present many such generators in the talk for ready implementation. An extensive empirical study shows that these large-order DX generators have passed the stringent Crush battery of the TestU01 package.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GEvolution, Condition-Specificity, and Regulatory Impact of Untranslated RNA and Transcriptional Dark Matter
    ¥DÁ¿¤H¡GDr. Joshua Rest¡]Department of Ecology and Evolution, University of Chicago¡^
    ®É¡@¶¡¡G96¦~12¤ë14¤é(¬P´Á¤­)¤W¤È10:00-10:50
    (¤W¤È10:50-11:10¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Expressed but untranslated regions (UTRs) of genes are now known to participate in gene regulation. Using a tiling microarray assay of genome-wide expression levels, we identify length variation of UTRs among different stress conditions in four yeast strains. We characterize the evolution of these condition-dependent length differences between strains, assess their potential impact on the regulatory evolution of stress response, and look for associations with nucleotide changes. It has also been observed that there is widespread transcription in the intergenic regions of eukaryotes, leading to the idea of transcriptional dark matter. We characterize the evolution of condition-specific intergenic expression, and assess the hypothesis that it represents neutral change due to gain and loss of spurious binding sites.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GOutlier Tissue Approach for Microarray Data Analysis
    ¥DÁ¿¤H¡GProf. Chen, Dung-Tsa (Department of Interdisciplinary Oncology Moffitt Cancer Center & Research Institute, University of South Florida)
    ®É¡@¶¡¡G96¦~12¤ë3¤é(¬P´Á¤@)¤U¤È14:00-14:50
    (¤U¤È13:40-14:00¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Screening for cancer risk in patients remains challenge even with radiographic and physical examinations. No reliable molecular screening tools are currently available that can identify the patients at high risk for cancer development or local recurrence. In this talk, I will describe a statistical outlier approach to identify high-risk normal tissues which while their pheno type looks like normal tissue, but their molecular signatures tend to have tumor-like gene profile. Simulation has yielded promising results. The approach is also successfully applied to a breast cancer data.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GEvolution of Multiple Hypothesis Testing in Genetic Studies
    ¥DÁ¿¤H¡G¿½¦¶§ö±Ð±Â (»OÆW¤j¾Ç¤½¦@½Ã¥Í¾Ç¨t)
    ®É¡@¶¡¡G96¦~11¤ë30¤é(¬P´Á¤­)¤W¤È10:40-11:30
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    The recent advancement of biotechnology and the announcement of human genome have made the genetic association studies possible and easier to conduct. It also opens a new era in statistical sciences. The challenge of testing simultaneously a large number of hypotheses in genomics has been receiving considerable attention. It differs from the traditional multiple comparisons performed after a significant overall test. The small sample size, the large number of tests, and the correlation within data have made the issue even more complex. Statisticians have tackled the problem from different angles. Several algorithms focused on selection of ordered p-values via a bottom-up or top-down procedure, possibly under a controlled false discovery rate (FDR); while some recommended a multi-stage procedure using data from different subjects at every stage, or starting with a smaller group of individuals and then augmenting the data in each of the rest stages. Recently, several researchers proposed to replace the standard null normal distribution with other dispersed ones for the statistics under the null or the alternative hypothesis. Alternatively, the use of Bayesian mixture model considers simultaneously the character of classifying the hypotheses and the general dependence among data. In this talk, we will discuss briefly the current development, introduce the Bayesian approach, and highlight some possible directions.

    (This is a joint work with Yu-Chung Wei and Shu-Hui Wen)
  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GModeling and Joint Estimation of Two Order-Restricted Contingent Valuation Scenarios
    ¥DÁ¿¤H¡G¦¿®¶ªF±Ð±Â (¬Fªv¤j¾Ç²Î­p¨t)
    ®É¡@¶¡¡G96¦~11¤ë2¤é(¬P´Á¤­)¤W¤È10:40-11:30
    (¤W¤È10:20-10:40¯ù·|©ó¥æ¤j²Î­p©Ò428«ÇÁ|¦æ)
    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    Nowadays more and more double-bounded dichotomous choice contingent valuation surveys ask subjects to respond to more than one WTP (willingness-to-pay) scenarios. Under such a circumstance, responses provided by a subject are clearly correlated, and the prices themselves might be inherently ordered as well. The former, despite being well recognized in the literature, is often ignored by practitioners. The latter, on the other hand, receives little attention. These are the two issues that need to be addressed. Additional issue that is worthy of attention is about the protest samples. In this study, we propose a model based on a new family of bivariate distributions to handle the three issues simultaneously. The model is also applied to elicit WTP for two weight-loss programs.

  • °ê¥ß¥æ³q¤j¾Ç¡B²MµØ¤j¾Ç ²Î­p¾Ç¬ã¨s©Ò ±MÃDºtÁ¿

    ÃD¡@¥Ø¡GParametric Robust Inferences for Correlated Ordinal Data
    ¥DÁ¿¤H¡G¹Q©v¤s±Ð±Â (¤¤¥¡¤j¾Ç²Î­p©Ò)
    ®É¡@¶¡¡G96¦~10¤ë19¤é(¬P´Á¤­)¤W¤È10:40-11:30
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    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    Abstract

    The aim of this talk is to introduce a parametric robust approach to making inferences about regression parameters for correlated ordinal response variables. The legitimacy of this novel approach requires no knowledge of the underlying joint distributions so long as their second moments exist. The efficacy of the proposed parametric method is demonstrated via simulations and the analyses of two real data sets.
    Key Words¡GCorrelated ordinal data; Proportional odds models; Robust likelihoods

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  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/7/3)

    ®É¡@¶¡¡G95¦~7¤ë3¤é(¬P´Á¤G)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G
    §õ¤å¶¯°|¤h (The James Watson Professor, Department of Ecology and Evolution, University of Chicago)

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    Why Biomedical Sciences need computational and IT scientists
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/7/2)

    ®É¡@¶¡¡G95¦~7¤ë2¤é(¬P´Á¤@)¤U¤È13:30-14:20

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G
    Wolfgang K. Hardle (Center for Applied Statistics and Economics, Humboldt-Universitat zu Berlin)

    Á¿¡@ÃD¡G
    Time Series Modelling with Semiparametric Factor Dynamics
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/6/8)

    ®É¡@¶¡¡G95¦~6¤ë8¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G§õª÷¤W³Õ¤h(Dept. of Biostatistics, St. Jude Children's Research Hospital)

    Á¿¡@ÃD¡GModeling Zero-Inflated Count Data with B-Splines and Its Applications
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/6/4)

    ®É¡@¶¡¡G95¦~6¤ë4¤é(¬P´Á¤@)¤U¤È13:30-14:20

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G¾G±©§µ±Ð±Â (Department of Statistics, University of Manitoba, Canada)

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    Single Variables Control Charts: An Overview
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/5/4)

    ®É¡@¶¡¡G95¦~5¤ë4¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G§õ§J¬L©Òªø (¤¤¬ã°|²Î­p©Ò)

    Á¿¡@ÃD¡GExtreme p-values in multiple hypothesis testing: the memoryless conversion approach
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/4/13)

    ®É¡@¶¡¡G95¦~4¤ë13¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡GProf. Seng-jaw Soong (University of Alabama at Birmingham, USA)

    Á¿¡@ÃD¡GMultivariate Modeling of Cancer Prognosis and Staging
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/3/23)

    ®É¡@¶¡¡G95¦~3¤ë23¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G±i¤ÉÀ·³Õ¤h (North Carolina State University, USA)

    Á¿¡@ÃD¡GA Stationary Stochastic Approximation Algorithm for Estimation in Generalized Linear Mixed Models
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (¦]¬G©µ¦Ü2007/3/16)

    ®É¡@¶¡¡G95¦~3¤ë9¤é(¬P´Á¤­)¤W¤È10:40-11:30 (¦]¬G©µ¦Ü2007/3/16)

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G¶Àºû´@±Ð±Â(University of Pennsylvania School of Medicine, USA)

    Á¿¡@ÃD¡GAnalysis of Local Recurrence and Distant Metastases in Early-Stage Breast Cancer Using a Mixture Markov Model
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/2/2)

    ®É¡@¶¡¡G95¦~2¤ë2¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G³¯´É§÷±Ð±Â(Department of Interdisciplinary Oncology Moffitt Cancer Center & Research Institute, University of South Florida)

    Á¿¡@ÃD¡GMicroarray Data Analysis in Affymetrix Gene Chips
  • ¤¤¥¡»È¦æ¯u¥Î°ê»Úª÷¿Ä±M·~¤H­û¤½§i (2007/1/12)

    ºØÃþ¡G²Î­p¾ÇºÓ¤h(¥ý¥H¿ì¨Æ­û¶i¥Î¡A¸g¦~²×¦Ò®ÖÁZÀuª@¥ô¥|µ¥±M­û)
    ³Õ¤h(°Æ¬ã¨s­û©Î¦Pµ¥Â¾¦ì) 2¦W

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  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2007/1/12)

    ®É¡@¶¡¡G96¦~1¤ë12¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G³¯¤å¾Ë±Ð±Â(Department of Mathematics, University of Miami, U.S.A.)

    Á¿¡@ÃD¡GOn the First Occurrence of Strings
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/12/29)

    ®É¡@¶¡¡G95¦~12¤ë29¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡GProf. Loon-Ching Tang ( ISE Department, National Singapore University)

    Á¿¡@ÃD¡GA Reliability Model for Hard Disk Drives
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/12/15)

    ®É¡@¶¡¡G95¦~12¤ë15¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G½²©ú¥Ð±Ð±Â¡]¤¤¬ã°|²Î­p©Ò¡^

    Á¿¡@ÃD¡GThe Optimal Rank Tests for Modal Direction
  • 2006¥æ³q¤j¾Ç²Î­p©Ò¡@µu´Á½Òµ{¤½§i (2006/12/03 ~ 2006/12/08)

    ®É¡@¶¡¡G95¦~12¤ë3¤é(¬P´Á¤é) ¦Ü 95¦~12¤ë8¤é(¬P´Á¤­)

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    ¥DÁ¿¤H¡GAlan Hopburn Welsh (¿D¬w°ê¥ß¤j¾Ç±Ð±Â)

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        Basic statistical theory
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        ( ºî¤@À] 427 «Ç )

        Large sample theory
        12 ¤ë 6 ¤é ( ¤T ) ¤W¤È 9:00~12:00

        ( ºî¤@À] 407 «Ç )

        Robustness
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        12 ¤ë 3 ¤é ( ¤é ) ¤W¤È 9:00~12:00 P-value
        12 ¤ë 8 ¤é ( ¤­ ) ¤U¤È 2:00~ 5:00 Tolerance interval, Sample set mapping

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  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/11/17)

    ®É¡@¶¡¡G95¦~11¤ë17¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G¥C¬F¥Á±Ð±Â¡]¤¤¬ã°|²Î­p©Ò¡^

    Á¿¡@ÃD¡GRegression Diagnostics for Functional Regression Models
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/11/3)

    ®É¡@¶¡¡G95¦~11¤ë3¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G§E²M²»±Ð±Â¡]¬Fªv¤j¾Ç²Î­p¾Ç¨t¡^

    Á¿¡@ÃD¡GA Permutation Test for Cluster Detection
  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/10/20)

    ®É¡@¶¡¡G95¦~10¤ë20¤é(¬P´Á¤­)¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G¤ý¨q·ë±Ð±Â¡]¤¤¬ã°|²Î­p©Ò ¡^

    Á¿¡@ÃD¡GExact Confidence Coefficients of Confidence Intervals for a Binomial Proportion
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    Ápµ¸¹q¸Ü¡G03-513-1334
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    ¤T¡B ¼f¬d¤è¦¡¡G2006 ¦~12 ¤ë31 ¤é¤î
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  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/9/29)

    ®É¡@¶¡¡G95¦~9¤ë29¤é(¬P´Á¤­) ¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G¶·¤W­^³Õ¤h¡]¤¤¬ã°|²Î­p©Ò ¡^

    Á¿¡@ÃD¡GPROC Analysis: Effect of Threshold Value for Diagnostic Test


  • ¥æ³q¤j¾Ç²Î­p¾Ç¬ã¨s©ÒºtÁ¿¤½§i (2006/9/15)

    ®É¡@¶¡¡G95¦~9¤ë15¤é(¬P´Á¤­) ¤W¤È10:40-11:30

    ¦a¡@ÂI¡G¥æ¤jºî¦X¤@À]427«Ç

    ¥DÁ¿¤H¡G §ù¾ÐµÓ±Ð±Â¡]¤¤¬ã°|²Î­p©Ò ¡^

    Á¿¡@ÃD¡G Beyond the Scree Plot

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