124,861 research outputs found
Going Beyond Counting First Authors in Author Co-citation Analysis
No full textThe present study examines one of the fundamental aspects of author co-citation analysis (ACA) - the way co-citation
counts are defined. Co-citation counting provides the data on which all subsequent statistical analyses and mappings
are based, and we compare ACA results based on two different types of co-citation counting - the traditional type that
only counts the first one among a cited work's authors on the one hand and a non-traditional type that takes into
account the first 5 authors of a cited work on the other hand. Results indicate that the picture produced through this non-traditional author co-citation counting contains more coherent author groups and is therefore considerably clearer. However, this picture represents fewer specialties in the research field being studied than that produced through the traditional first-author co-citation counting when the same number of top-ranked authors is selected and analyzed. Reasons for these effects are discussed
Dispelling the Myths Behind First-author Citation Counts
No full textWe conducted a full-scale evaluative citation analysis study of scholars in the XML research field to explore just how different from each other author rankings resulting from different citation counting methods actually are, and to demonstrate the capability of emerging data and tools on the Web in supporting more realistic citation counting methods. Our results contest some common arguments for the continued
use of first-author citation counts in the evaluation of scholars, such as high correlations between author rankings by first-author citation counts and other citation
counting methods, and high costs of using more realistic citation counting methods that are not well-supported by the ISI databases. It is argued that increasingly available digital full text research papers make it possible for citation analysis studies to go beyond what the ISI databases have directly supported and to employ more
sophisticated methods
The EM-algorithm for modeling Serial Analysis of Gene Expression (SAGE) data
No full textSerial Analysis of Gene Expression (SAGE), a technique that has been developed at Johns
Hopkins University in the USA, allows the analysis of overall gene expression patterns. It
is an open platform because SAGE does not require a preexisting clone, unlike microarrays.
So SAGE can be used for the identification and quantification of known genes as well as new genes. A SAGE experiment, from a statistical points of view, consists of the following 7 steps: 1. Extract a sample of mRNA fragments from a biological sample.
2. Convert the mRNA fragment into cDNA clones. 3. Generate tags by cutting 10 or 17 base long segments from a certain site of cDNA. These tags are what we call the true tags. 4. Apply the PCR (Polymerase Chain Reaction) procedure to boost the counts of the tags. 5. Link the tags to form long sequences. 6. Take a sample of those sequences. 7. Read off tag counts by sequencing these chosen sequences. The resulting tags are called sequenced tags and the resulting counts are the observed counts.
Note that no true tags are lost before, during or after sequencing, hence the number of se-
quenced tags is equal to the number of true tags. In the following sections we will assume
that the true tags uniquely identify mRNA fragments that are present in the biological sample. The result of a SAGE experiment, called a SAGE library, contains the observed counts. Hence a SAGE experiment can only measure the expression levels of the tags. We can get the gene expression levels from a SAGE library by mapping the tags onto the genes. The aspects of SAGE experiments that bias the outcomes have been studied by simulating libraries by Stollberg et al. (2000). The following four sources of errors are considered: (1) sampling errors in tag selection; (2) sequencing errors;
(3) non uniqueness of tag sequences; and
(4) non randomness of DNA sequences.
The authors have provided a maximum likelihood approach to estimate the number of unique transcripts and their frequency distribution. In what follows, we will focus on sequencing errors. Sequencing errors have a large impact on the outcome of a SAGE experiment: non-existing tags may be introduced at low abundance and the real abundance of the other tags may decrease.
Colinge and Feger (2001) introduced an approach to identify tags whose abundance is biased by sequencing errors. Their approach is based on a concept of neighbourhood, i.e. abundant tags can contaminate tags whose sequence is very close. They assume constant error probabilities and use matrix inversion to correct for sequencing errors.
There are also more biological approaches to the problem of sequencing errors as in Blades et al. (2004a,b). In Blades et al. (2004a), the fact that frequency distributions of tags display a regularity across cell types and species is used to: • automatically discount low counts that are not reliable for the comparison of expression levels across conditions for a specific gene; • to transform the tag counts to a scale that provides a more reliable correlation and clustering of genome-wide expression profiles. They state that the transformation enhances the ability to distinguish between signal and noise in SAGE data. Blades et al. (2004b) observed a linear relationship between the copy
number of a given tag and the number of observed tags which differ from the given tag by a single base. By transforming the slope of this relationship, an estimate of the sequencing error rate can be found. Akmaev and Wang (2004) estimated error rates based on a mathematical model that includes the PCR and sequencing error contributions. About 3.5% of Long SAGE tags (10-17 base pair tags) will inherit errors from the PCR amplification and 17.3% of the Long SAGE
tags will have sequencing errors. Beissbarth et al. (2004) introduced a statistical model for the propagation of sequencing errors and proposed an Expectation-Maximization (EM) algorithm to correct for the sequencing errors given a library of observed sequences and base-calling error estimates. The
suggested correction method adjusts the tag counts to be closer to the true counts and the
bias introduced by the sequencing errors can be partly corrected. In the article, they make
use of the sequence neighbourhood of SAGE tags. This means that they assume that sequencing errors can only come from the first order neighbours tags. First order neighbours tags are tags that differ from each other by only 1 nucleotide, e.g. AAAA and AAAC are first order neighbour tags. The authors simulate the true tag counts by sampling from a Poisson distribution with mean pλ, with p the proportion of a tag in the library and λ a parameter for setting the size of the library. An observed tag sequence is generated from a true tag sequence using the simulated quality values (given by a base-calling program and in function of the probability of
a base-calling error) of the true tag sequence as the multinomial probabilities, i.e. replacing
each base with either one of the three bases with the probability specified by the sequencing quality value of that base. The counts of the observed tags are then summed to represent the observed tags. The implementation of the algorithm is done in R.
We also propose a statistical model for the propagation of sequencing errors in the case
that we have multiple SAGE libraries and correct for the sequencing error through an EM
algorithm by using a similar strategy as Beissbarth et al. (2004). We use MATLAB for the implementation. There are, however, some differences between our method and the one developed by Beiss-brath et al. (2004). We assume that the true tag counts follow a multinomial distribution with parameters π and N, where π is the vector of probabilities that represent the relative expression levels of the DNA fragment and N is the number of true tags. The error estimates which we propose are partly based on the estimate given in Akmaev and Wang (2004). Another difference is that we assume that the sequencing errors are such that a tag can be misread as one of all possible tags, instead of only restricting this to the first order neighbours. Finally, in paper of Beissbarth et al. (2004), they work with Long SAGE sequences, while we work with sequences of four base pairs because we do not use the restriction of the first order neighbours. In section 2, we explain the notation and the settings that we will use throughout this thesis. In section 3, we give a detailed mathematical description of the EM algorithm with the expressions for the estimates of the expression probabilities π and the corresponding Variance-Covariance matrix. In section 4, we simulate SAGE libraries to study the following: • the potential gain in terms of bias when we use estimates obtained by the EM algorithm instead of the observed expression probabilities; • the potential gain in terms of bias when we use multiple libraries instead of a single library;
• the effect of the probabilities of sequencing errors; • the comparison of the bias using our method and using the method of Beissbarth et
al. (2004). The results of the simulations are given in section 5
The EM-algorithm for modeling Serial Analysis of Gene Expression (SAGE) data
No full textSerial Analysis of Gene Expression (SAGE), a technique that has been developed at Johns
Hopkins University in the USA, allows the analysis of overall gene expression patterns. It
is an open platform because SAGE does not require a preexisting clone, unlike microarrays.
So SAGE can be used for the identification and quantification of known genes as well as new genes. A SAGE experiment, from a statistical points of view, consists of the following 7 steps: 1. Extract a sample of mRNA fragments from a biological sample.
2. Convert the mRNA fragment into cDNA clones. 3. Generate tags by cutting 10 or 17 base long segments from a certain site of cDNA. These tags are what we call the true tags. 4. Apply the PCR (Polymerase Chain Reaction) procedure to boost the counts of the tags. 5. Link the tags to form long sequences. 6. Take a sample of those sequences. 7. Read off tag counts by sequencing these chosen sequences. The resulting tags are called sequenced tags and the resulting counts are the observed counts.
Note that no true tags are lost before, during or after sequencing, hence the number of se-
quenced tags is equal to the number of true tags. In the following sections we will assume
that the true tags uniquely identify mRNA fragments that are present in the biological sample. The result of a SAGE experiment, called a SAGE library, contains the observed counts. Hence a SAGE experiment can only measure the expression levels of the tags. We can get the gene expression levels from a SAGE library by mapping the tags onto the genes. The aspects of SAGE experiments that bias the outcomes have been studied by simulating libraries by Stollberg et al. (2000). The following four sources of errors are considered: (1) sampling errors in tag selection; (2) sequencing errors;
(3) non uniqueness of tag sequences; and
(4) non randomness of DNA sequences.
The authors have provided a maximum likelihood approach to estimate the number of unique transcripts and their frequency distribution. In what follows, we will focus on sequencing errors. Sequencing errors have a large impact on the outcome of a SAGE experiment: non-existing tags may be introduced at low abundance and the real abundance of the other tags may decrease.
Colinge and Feger (2001) introduced an approach to identify tags whose abundance is biased by sequencing errors. Their approach is based on a concept of neighbourhood, i.e. abundant tags can contaminate tags whose sequence is very close. They assume constant error probabilities and use matrix inversion to correct for sequencing errors.
There are also more biological approaches to the problem of sequencing errors as in Blades et al. (2004a,b). In Blades et al. (2004a), the fact that frequency distributions of tags display a regularity across cell types and species is used to: • automatically discount low counts that are not reliable for the comparison of expression levels across conditions for a specific gene; • to transform the tag counts to a scale that provides a more reliable correlation and clustering of genome-wide expression profiles. They state that the transformation enhances the ability to distinguish between signal and noise in SAGE data. Blades et al. (2004b) observed a linear relationship between the copy
number of a given tag and the number of observed tags which differ from the given tag by a single base. By transforming the slope of this relationship, an estimate of the sequencing error rate can be found. Akmaev and Wang (2004) estimated error rates based on a mathematical model that includes the PCR and sequencing error contributions. About 3.5% of Long SAGE tags (10-17 base pair tags) will inherit errors from the PCR amplification and 17.3% of the Long SAGE
tags will have sequencing errors. Beissbarth et al. (2004) introduced a statistical model for the propagation of sequencing errors and proposed an Expectation-Maximization (EM) algorithm to correct for the sequencing errors given a library of observed sequences and base-calling error estimates. The
suggested correction method adjusts the tag counts to be closer to the true counts and the
bias introduced by the sequencing errors can be partly corrected. In the article, they make
use of the sequence neighbourhood of SAGE tags. This means that they assume that sequencing errors can only come from the first order neighbours tags. First order neighbours tags are tags that differ from each other by only 1 nucleotide, e.g. AAAA and AAAC are first order neighbour tags. The authors simulate the true tag counts by sampling from a Poisson distribution with mean pλ, with p the proportion of a tag in the library and λ a parameter for setting the size of the library. An observed tag sequence is generated from a true tag sequence using the simulated quality values (given by a base-calling program and in function of the probability of
a base-calling error) of the true tag sequence as the multinomial probabilities, i.e. replacing
each base with either one of the three bases with the probability specified by the sequencing quality value of that base. The counts of the observed tags are then summed to represent the observed tags. The implementation of the algorithm is done in R.
We also propose a statistical model for the propagation of sequencing errors in the case
that we have multiple SAGE libraries and correct for the sequencing error through an EM
algorithm by using a similar strategy as Beissbarth et al. (2004). We use MATLAB for the implementation. There are, however, some differences between our method and the one developed by Beiss-brath et al. (2004). We assume that the true tag counts follow a multinomial distribution with parameters π and N, where π is the vector of probabilities that represent the relative expression levels of the DNA fragment and N is the number of true tags. The error estimates which we propose are partly based on the estimate given in Akmaev and Wang (2004). Another difference is that we assume that the sequencing errors are such that a tag can be misread as one of all possible tags, instead of only restricting this to the first order neighbours. Finally, in paper of Beissbarth et al. (2004), they work with Long SAGE sequences, while we work with sequences of four base pairs because we do not use the restriction of the first order neighbours. In section 2, we explain the notation and the settings that we will use throughout this thesis. In section 3, we give a detailed mathematical description of the EM algorithm with the expressions for the estimates of the expression probabilities π and the corresponding Variance-Covariance matrix. In section 4, we simulate SAGE libraries to study the following: • the potential gain in terms of bias when we use estimates obtained by the EM algorithm instead of the observed expression probabilities; • the potential gain in terms of bias when we use multiple libraries instead of a single library;
• the effect of the probabilities of sequencing errors; • the comparison of the bias using our method and using the method of Beissbarth et
al. (2004). The results of the simulations are given in section 5
Pragmatic Case Studies as a Source of Unity in Applied Psychology
No full textTo unify or not to unify applied psychology: that is the question. In this article we review pendulum swings in the historical efforts to answer this question—from a comprehensive, positivist, “top-down,” deductive yes between the 1930s and the early 60s, to a postmodern no since then. A rationale and proposal for a limited, “bottom-up,” inductive yes in applied psychology is then presented, employing a case-based paradigm that integrates both positivist and postmodern themes and components. This paradigm is labeled “pragmatic psychology” and, its specific use of case studies, the “Pragmatic Case Study Method” (“PCS Method”). We call for the creation of peer-reviewed journal-databases of pragmatic case studies as a foundational source of unifying applied knowledge in our discipline. As one example, the potential of the PCS Method for unifying different angles of theoretical regard is illustrated in an area of applied psychology, psychotherapy, via the case of Mrs. B. The article then turns to the broader historical and epistemological arguments for the unifying nature of the PCS Method in both applied and basic psychology.Peer reviewe
Dr. Edwin Wright Collection: Author Unknown
No full textNotes - The author relates several short stories about his neighbours including Alex McDonell, homesteading and life around Meanook and Athabasca (1 page
Appropriate Similarity Measures for Author Cocitation Analysis
No full textWe provide a number of new insights into the methodological discussion about author cocitation analysis. We first argue that the use of the Pearson correlation for measuring the similarity between authors’ cocitation profiles is not very satisfactory. We then discuss what kind of similarity measures may be used as an alternative to the Pearson correlation. We consider three similarity measures in particular. One is the well-known cosine. The other two similarity measures have not been used before in the bibliometric literature. Finally, we show by means of an example that our findings have a high practical relevance.information science;Pearson correlation;cosine;similarity measure;author cocitation analysis
Measurement of the ratio of branching fractions B(B0→K∗0γ )/B(B0s→φγ ) and the directCP asymmetry inB 0→K∗0γ
No full textThe ratio of branching fractions of the radiative B decays B0→K⁎0γ and B0s→ϕγ has been measured using an integrated luminosity of 1.0 fb−1 of pp collision data collected by the LHCb experiment at a centre-of-mass energy of s√=7TeV. The value obtained is
B(B0→K⁎0γ)B(B0s→ϕγ)=1.23±0.06(stat.)±0.04(syst.)±0.10(fs/fd),
where the first uncertainty is statistical, the second is the experimental systematic uncertainty and the third is associated with the ratio of fragmentation fractions fs/fd. Using the world average value for B(B0→K⁎0γ), the branching fraction B(B0s→ϕγ) is measured to be (3.5±0.4)×10−5.
The direct CP asymmetry in B0→K⁎0γ decays has also been measured with the same data and found to be
ACP(B0→K⁎0γ)=(0.8±1.7(stat.)±0.9(syst.))%.
Both measurements are the most precise to date and are in agreement with the previous experimental results and theoretical expectations
The construction of Karen Karnak: The multi-author-function
No full textThis thesis is situated within the comparatively recent developments of Web 2.0 and the emergence of interactive WikiMedia, and explores the mode of authorship within a Read/Write culture compared to that of a Read/Only tradition. The hypothesis of this study is that the role of the audience has become merged with the author, and as such, represents new functions and attributes, distinct from a more conventional concept of authorship, in which the roles of audience and author are more separate. Read/Write and participatory culture, as defined by this study, is focused on collaboration, and includes the influences of D.I.Y. culture, Open-Source practices and the production of text by multiple authors. Multi-authorship presents a re-thinking of several concepts which support the notion of the individual author, since the focus of multi-authorship is not on attribution and ownership of a finished text, but on the continued malleability of a text. Modes of multi-authorship, demonstrated in the use of the pseudonyms Alan Smithee and Karen Eliot, represent declarative authors whose names signify multiple origins, whilst concurrently indicating a distinct body of work. The function of these names form an important context to this study, since primary research involves the construction of an experimental mode of multi-authorship utilising WikiMedia technology and the interaction of thirty nine participants, who are invited to create a body of work under the collective pseudonym Karen Karnak. The data generated by this experiment is analysed using aspects of Michel Foucault's author-function to identify and determine power structures inherent in the WikiMedia context. The interplay of power structures, including concepts such as identity, ownership and the body of work, affect the resulting mode of authorship and contribute to the construction of Karen Karnak, suggesting further areas of research into the emerging multi-author
Branching fraction and CP asymmetry of the decays B+→K0Sπ+ and B+→K0SK+
No full textAn analysis of B+ → K0
Sπ+ and B+ → K0
S K+ decays is performed with the LHCb experiment. The pp
collision data used correspond to integrated luminosities of 1 fb−1 and 2 fb−1 collected at centre-ofmass
energies of
√
s = 7 TeV and
√
s = 8 TeV, respectively. The ratio of branching fractions and the
direct CP asymmetries are measured to be B(B+ → K0
S K+
)/B(B+ → K0
Sπ+
) = 0.064 ± 0.009 (stat.) ±
0.004 (syst.), ACP(B+ → K0
Sπ+
) = −0.022 ± 0.025 (stat.) ± 0.010 (syst.) and ACP(B+ → K0
S K+
) =
−0.21 ± 0.14 (stat.) ± 0.01 (syst.). The data sample taken at
√
s = 7 TeV is used to search for
B+
c
→ K0
S K+ decays and results in the upper limit ( fc · B(B+
c
→ K0
S K+
))/( fu · B(B+ → K0
Sπ+
)) <
5.8 × 10−2 at 90% confidence level, where fc and fu denote the hadronisation fractions of a ¯b
quark
into a B+
c or a B+ meson, respectively
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