The present study considers the role of adjectives and adverbs in stylometric analysis and authorship attribution. Adjectives and adverbs allow both for variations in placement and order (adverbs) ...and variations in type (adjectives). This preliminary study examines a collection of 25 English-language blogs taken from the Schler Blog corpus, and the Project Gutenberg corpus with specific emphasis on 3 works. Within the blog corpora, the first and last 100 lines were extracted for the purpose of analysis. Project Gutenberg corpora were used in full. All texts were processed and part-of-speech tagged using the Python NLTK package. All adverbs were classified as sentence-initial, preverbal, interverbal, postverbal, sentence-final, or none-of-the-above. The adjectives were classified into types according to the universal English type hierarchy (Cambridge Dictionary Online,
2021
; Annear,
1964
) manually by one of the authors. Ambiguous adjectives were classified according to their context. For the adverbs, the initial samples were paired and used as training data to attribute the final samples. This resulted in 600 trials under each of five experimental conditions. We were able to attribute authorship with an average accuracy of 9.7% greater than chance across all five conditions. Confirmatory experiments are ongoing with a larger sample of English-language blogs. This strongly suggests that adverbial placement is a useful and novel idiolectal variable for authorship attribution (Juola et al.,
2021
). For the adjective, differences were found in the type of adjective used by each author. Percent use of each type varied based upon individual preference and subject-matter (e.g. Moby Dick had a large number of adjectives related to size and color). While adverbial order and placement are highly variable, adjectives are subject to rigid restrictions that are not violated across texts and authors. Stylometric differences in adjective use generally involve the type and category of adjectives preferred by the author. Future investigation will focus, likewise, on whether adverbial variation is similarly analyzable by type and category of adverb.
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EMUNI, FIS, FZAB, GEOZS, GIS, IJS, IMTLJ, KILJ, KISLJ, MFDPS, NLZOH, NUK, OILJ, PNG, SAZU, SBCE, SBJE, SBMB, SBNM, UKNU, UL, UM, UPUK, VKSCE, ZAGLJ
Observational studies link statin therapy with improved outcomes in patients with severe sepsis.
To test whether atorvastatin therapy affects biologic and clinical outcomes in critically ill patients ...with severe sepsis.
Phase II, multicenter, prospective, randomized, double-blind, placebo-controlled trial stratified by site and prior statin use. A cohort of 250 critically ill patients (123 statins, 127 placebo) with severe sepsis were administrated either atorvastatin (20 mg daily) or matched placebo.
There was no difference in IL-6 concentrations (primary end point) between the atorvastatin and placebo groups (P = 0.76) and no interaction between treatment group and time to suggest that the groups behaved differently over time (P = 0.26). Baseline plasma IL-6 was lower among previous statin users (129 87-191 vs. 244 187-317 pg/ml; P = 0.01). There was no difference in length of stay, change in Sequential Organ Failure Assessment scores or mortality at intensive care unit discharge, hospital discharge, 28- or 90-day (15% vs. 19%), or adverse effects between the two groups. Cholesterol was lower in patients treated with atorvastatin (2.4 0.07 vs. 2.6 0.06 mmol/L; P = 0.006). In the predefined group of 77 prior statin users, those randomized to placebo had a greater 28-day mortality (28% vs. 5%; P = 0.01) compared with those who received atorvastatin. The difference was not statistically significant at 90 days (28% vs. 11%; P = 0.06).
Atorvastatin therapy in severe sepsis did not affect IL-6 levels. Prior statin use was associated with a lower baseline IL-6 concentration and continuation of atorvastatin in this cohort was associated with improved survival. Clinical trial registered with the Australian New Zealand Clinical Trials Registry (ACTRN 12607000028404).
A Josephson binary counter using single-flux quanta transitions of DC SQUIDs (superconducting quantum interference devices) has been fabricated using an eight-level NbN-based process. High-speed ...binary division has been demonstrated at 4.2 K, with single-cell counting observed at 60 GHz using the Josephson voltage-to-frequency relationship. Count rate was primarily limited by conservative process and design rules. The counter was designed for operation at 4.2 K. At 8-10 K, the beta /sub L/ of the SQUIDs would not allow operation, though the junction characteristics were good.< >
Vaccination against viruses has rarely been associated with Guillain-Barré syndrome (GBS), and an association with the COVID-19 vaccine is unknown. We performed a population-based study of National ...Health Service data in England and a multicentre surveillance study from UK hospitals to investigate the relationship between COVID-19 vaccination and GBS. Firstly, case dates of GBS identified retrospectively in the National Immunoglobulin Database from 8 December 2021 to 8 July 2021 were linked to receipt dates of COVID-19 vaccines using data from the National Immunisation Management System in England. For the linked dataset, GBS cases temporally associated with vaccination within a 6-week risk window of any COVID-19 vaccine were identified. Secondly, we prospectively collected incident UK-wide (four nations) GBS cases from 1 January 2021 to 7 November 2021 in a separate UK multicentre surveillance database. For this multicentre UK-wide surveillance dataset, we explored phenotypes of reported GBS cases to identify features of COVID-19 vaccine-associated GBS. Nine hundred and ninety-six GBS cases were recorded in the National Immunoglobulin Database from January to October 2021. A spike of GBS cases above the 2016-2020 average occurred in March-April 2021. One hundred and ninety-eight GBS cases occurred within 6 weeks of the first-dose COVID-19 vaccination in England 0.618 cases per 100,000 vaccinations; 176 ChAdOx1 nCoV-19 (AstraZeneca), 21 tozinameran (Pfizer) and one mRNA-1273 (Moderna). The 6-week excess of GBS (compared to the baseline rate of GBS cases 6-12 weeks after vaccination) occurred with a peak at 24 days post-vaccination; first-doses of ChAdOx1 nCoV-19 accounted for the excess. No excess was seen for second-dose vaccination. The absolute number of excess GBS cases from January-July 2021 was between 98-140 cases for first-dose ChAdOx1 nCoV-19 vaccination. First-dose tozinameran and second-dose of any vaccination showed no excess GBS risk. Detailed clinical data from 121 GBS patients were reported in the separate multicentre surveillance dataset during this timeframe. No phenotypic or demographic differences identified between vaccine-associated and non-vaccinated GBS cases occurring in the same timeframe. Analysis of the linked NID/NIMS dataset suggested that first-dose ChAdOx1 nCoV-19 vaccination is associated with an excess GBS risk of 0.576 (95% confidence interval 0.481-0.691) cases per 100 000 doses. However, examination of a multicentre surveillance dataset suggested that no specific clinical features, including facial weakness, are associated with vaccination-related GBS compared to non-vaccinated cases. The pathogenic cause of the ChAdOx1 nCoV-19 specific first dose link warrants further study.
Background
Postal and electronic questionnaires are widely used for data collection in epidemiological studies but non‐response reduces the effective sample size and can introduce bias. Finding ways ...to increase response to postal and electronic questionnaires would improve the quality of health research.
Objectives
To identify effective strategies to increase response to postal and electronic questionnaires.
Search methods
We searched 14 electronic databases to February 2008 and manually searched the reference lists of relevant trials and reviews, and all issues of two journals. We contacted the authors of all trials or reviews to ask about unpublished trials. Where necessary, we also contacted authors to confirm methods of allocation used and to clarify results presented. We assessed the eligibility of each trial using pre‐defined criteria.
Selection criteria
Randomised controlled trials of methods to increase response to postal or electronic questionnaires.
Data collection and analysis
We extracted data on the trial participants, the intervention, the number randomised to intervention and comparison groups and allocation concealment. For each strategy, we estimated pooled odds ratios (OR) and 95% confidence intervals (CI) in a random‐effects model. We assessed evidence for selection bias using Egger's weighted regression method and Begg's rank correlation test and funnel plot. We assessed heterogeneity among trial odds ratios using a Chi2 test and the degree of inconsistency between trial results was quantified using the I2 statistic.
Main results
Postal
We found 481 eligible trials. The trials evaluated 110 different ways of increasing response to postal questionnaires. We found substantial heterogeneity among trial results in half of the strategies. The odds of response were at least doubled using monetary incentives (odds ratio 1.87; 95% CI 1.73 to 2.04; heterogeneity P < 0.00001, I2 = 84%), recorded delivery (1.76; 95% CI 1.43 to 2.18; P = 0.0001, I2 = 71%), a teaser on the envelope ‐ e.g. a comment suggesting to participants that they may benefit if they open it (3.08; 95% CI 1.27 to 7.44) and a more interesting questionnaire topic (2.00; 95% CI 1.32 to 3.04; P = 0.06, I2 = 80%). The odds of response were substantially higher with pre‐notification (1.45; 95% CI 1.29 to 1.63; P < 0.00001, I2 = 89%), follow‐up contact (1.35; 95% CI 1.18 to 1.55; P < 0.00001, I2 = 76%), unconditional incentives (1.61; 1.36 to 1.89; P < 0.00001, I2 = 88%), shorter questionnaires (1.64; 95% CI 1.43 to 1.87; P < 0.00001, I2 = 91%), providing a second copy of the questionnaire at follow up (1.46; 95% CI 1.13 to 1.90; P < 0.00001, I2 = 82%), mentioning an obligation to respond (1.61; 95% CI 1.16 to 2.22; P = 0.98, I2 = 0%) and university sponsorship (1.32; 95% CI 1.13 to 1.54; P < 0.00001, I2 = 83%). The odds of response were also increased with non‐monetary incentives (1.15; 95% CI 1.08 to 1.22; P < 0.00001, I2 = 79%), personalised questionnaires (1.14; 95% CI 1.07 to 1.22; P < 0.00001, I2 = 63%), use of hand‐written addresses (1.25; 95% CI 1.08 to 1.45; P = 0.32, I2 = 14%), use of stamped return envelopes as opposed to franked return envelopes (1.24; 95% CI 1.14 to 1.35; P < 0.00001, I2 = 69%), an assurance of confidentiality (1.33; 95% CI 1.24 to 1.42) and first class outward mailing (1.11; 95% CI 1.02 to 1.21; P = 0.78, I2 = 0%). The odds of response were reduced when the questionnaire included questions of a sensitive nature (0.94; 95% CI 0.88 to 1.00; P = 0.51, I2 = 0%).
Electronic
We found 32 eligible trials. The trials evaluated 27 different ways of increasing response to electronic questionnaires. We found substantial heterogeneity among trial results in half of the strategies. The odds of response were increased by more than a half using non‐monetary incentives (1.72; 95% CI 1.09 to 2.72; heterogeneity P < 0.00001, I2 = 95%), shorter e‐questionnaires (1.73; 1.40 to 2.13; P = 0.08, I2 = 68%), including a statement that others had responded (1.52; 95% CI 1.36 to 1.70), and a more interesting topic (1.85; 95% CI 1.52 to 2.26). The odds of response increased by a third using a lottery with immediate notification of results (1.37; 95% CI 1.13 to 1.65), an offer of survey results (1.36; 95% CI 1.15 to 1.61), and using a white background (1.31; 95% CI 1.10 to 1.56). The odds of response were also increased with personalised e‐questionnaires (1.24; 95% CI 1.17 to 1.32; P = 0.07, I2 = 41%), using a simple header (1.23; 95% CI 1.03 to 1.48), using textual representation of response categories (1.19; 95% CI 1.05 to 1.36), and giving a deadline (1.18; 95% CI 1.03 to 1.34). The odds of response tripled when a picture was included in an e‐mail (3.05; 95% CI 1.84 to 5.06; P = 0.27, I2 = 19%). The odds of response were reduced when "Survey" was mentioned in the e‐mail subject line (0.81; 95% CI 0.67 to 0.97; P = 0.33, I2 = 0%), and when the e‐mail included a male signature (0.55; 95% CI 0.38 to 0.80; P = 0.96, I2 = 0%).
Authors' conclusions
Health researchers using postal and electronic questionnaires can increase response using the strategies shown to be effective in this systematic review.
Postal questionnaires are widely used for data collection in epidemiological studies but non-response reduces the effective sample size and can introduce bias. Finding ways to increase response rates ...to postal questionnaires would improve the quality of health research.
To identify effective strategies to increase response rates to postal questionnaires.
We aimed to find all randomised controlled trials of strategies to increase response rates to postal questionnaires. We searched 14 electronic databases to February 2003 and manually searched the reference lists of relevant trials and reviews, and all issues of two journals. We contacted the authors of all trials or reviews to ask about unpublished trials. Where necessary, authors were also contacted to confirm methods of allocation used and to clarify results presented. We assessed the eligibility of each trial using pre-defined criteria.
Randomised controlled trials of methods to increase response rates to postal questionnaires.
We extracted data on the trial participants, the intervention, the number randomised to intervention and comparison groups and allocation concealment. For each strategy, we estimated pooled odds ratios and 95% confidence intervals in a random effects model. Evidence for selection bias was assessed using Egger's weighted regression method and Begg's rank correlation test and funnel plot. Heterogeneity among trial odds ratios was assessed using a chi-square test at a 5% significance level and the degree of inconsistency between trial results was quantified using I(2).
We found 372 eligible trials. The trials evaluated 98 different ways of increasing response rates to postal questionnaires and for 62 of these the combined trials included over 1,000 participants. We found substantial heterogeneity among trial results in half of the strategies. The odds of response were at least doubled using monetary incentives (odds ratio 1.99, 95% CI 1.81 to 2.18; heterogeneity p<0.00001, I(2)=78%), recorded delivery (2.04, 1.60 to 2.61; p=0.0004, I(2)=69%), a teaser on the envelope - e.g. a comment suggesting to participants that they may benefit if they open it (3.08, 1.27 to 7.44) and a more interesting questionnaire topic (2.44, 1.99 to 3.01; p=0.74, I(2)=0%). The odds of response were substantially higher with pre-notification (1.50, 1.29 to 1.74; p<0.00001, I(2)=90%), follow-up contact (1.44, 1.25 to 1.65; p<0.0001, I(2)=68%), unconditional incentives (1.61, 1.27 to 2.04; p<0.00001, I(2)=91%), shorter questionnaires (1.73, 1.47 to 2.03; p<0.00001, I(2)=93%), providing a second copy of the questionnaire at follow-up (1.51, 1.13 to 2.00; p<0.00001, I(2)=83%), mentioning an obligation to respond (1.61, 1.16 to 2.22; p=0.98, I(2)=0%) and university sponsorship (1.32, 1.13 to 1.54; p<0.00001, I(2)=83%). The odds of response were also increased with non-monetary incentives (1.13, 1.07 to 1.21; p<0.00001, I(2)=71%), personalised questionnaires (1.16, 1.07 to 1.26; p<0.00001, I(2)=67%), use of coloured as opposed to blue or black ink (1.39, 1.16 to 1.67), use of stamped return envelopes as opposed to franked return envelopes (1.29, 1.18 to 1.42; p<0.00001, I(2)=72%), an assurance of confidentiality (1.33, 1.24 to 1.42) and first class outward mailing (1.12, 1.02 to 1.23). The odds of response were reduced when the questionnaire included questions of a sensitive nature (0.94, 0.88 to 1.00; p=0.51, I(2)=0%), when questionnaires began with the most general questions (0.80, 0.67 to 0.96), or when participants were offered the opportunity to opt out of the study (0.76, 0.65 to 0.89; p=0.46, I(2)=0%).
Health researchers using postal questionnaires can increase response rates using the strategies shown to be effective in this systematic review.
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NUK, OILJ, UL, UM, UPUK, VSZLJ
Abstract
Objectives
To assess the performance of the EULAR/ACR idiopathic inflammatory myopathies (IIMs) classification criteria in a cohort of incident IIM cases and examine how criteria-assigned ...IIM subtype correlates with expert opinion.
Methods
Adults with newly diagnosed IIM attending Salford Royal NHS Foundation Trust were identified over a 10 year period. A retrospective review of all putative cases was performed and those fulfilling a consensus expert opinion diagnosis of IIM were included. Clinical, serological and histological data were collected and each case was assigned a single IIM subtype. The EULAR/ACR classification criteria were then applied and sensitivity, specificity and positive and negative predictive values were calculated, presented with 95% CIs.
Results
A total of 1637 cases were screened, with 255 consensus expert opinion IIM cases ultimately identified. Applying the EULAR/ACR classification criteria, the sensitivity to diagnose an IIM was 99.6% (95% CI 97.2, 100) and 80.9% (95% CI 76.0, 85.8) for the criteria cut-points of probable and definite diagnoses, respectively. In 94/255 cases the IIM subtype differed between consensus expert opinion and classification criteria, most strikingly in the group subtyped as PM by the EULAR/ACR criteria, where there was discrepancy in the majority (i.e. in 87/161).
Conclusion
The EULAR/ACR criteria performed with high sensitivity in identifying IIM in this external cohort of incident IIM. However, substantial disagreements arose between consensus expert opinion and the criteria regarding IIM subtype assignments, resulting in a large proportion of criteria-assigned cases of PM having heterogeneous features. These results may have important implications for future use of these criteria in subsequent research.
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