dataesr/scientific-paragraphs-categorization huggingface dataset:
Introduction Research on ecosystem services (ES), the contribution of ecosystems to human wellbeing  (TEEB, 2010) , is often claimed to inform policy and decisions in various contexts such as biodiversity conservation, natural resource management, and spatial planning  (Daily et al. , 2009; Laurans and Mermet, 2014; Martinez-Harms et al. , 2015). Decision makers are increasingly interested in ES assessments  (Maes et al. , 2016; Pascual et al. , 2017). Indicators to track and communicate trends in the quantity and quality of ES form a crucial foundation for these assessments  (Ash et al. , 2010; Layke et al. , 2012). From the onset of ES assessments, the importance of developing appropriate indicators has been recognised, and many ES indicators and corresponding datasets have been developed, applied, tested and reviewed.
Such involvement is often desired by funding agencies, such as in the Niraj-MAES case study. The involvement of local experts can be considered to assist in gaining a systems understanding, when available literature is insufficient (Niraj-MAES). A particular challenge with regard to this criterion are indicators for cultural ES, which are so far not consistently defined and assessed (UK NEA cultural ES). One can also increase credibility by ensuring that the indicator is backed by the scientific literature. Credible indicators adhere to agreed scientific methods and available data sets where possible  (Layke et al. , 2012)  and make an assessment reproducible and reliable (La  Rosa et al. , 2016). Although a relatively simple literature review can contribute to ensuring this criterion is met, many case studies employed a combination of literature review and expert elicitation.
P. Flexible The indicator can be revisited and updated, if required To account for future realities in which meanings, values and people's behaviours change in response to economic, technological, social, political and cultural drivers (UK NEA 2011). We note that if a conceptual framework of an ES assessment has been co-developed by scientists and decision makers, the selected indicators are more likely to also be perceived as credible and salient (Niraj-MAES). Consequently, a purely scientifically developed conceptual framework likely lacks salience. Indicators that are quantifiable and backed up by high data quality are generally perceived as credible. High quality data can relate to whether it has been processed consistently and reliably, and whether it has been normalized and disaggregated  (Layke et al.
, 2014) , but not in disaggregated, processed or normalized form  (Layke et al. , 2012). In addition, availability can depend on whether the data is publicly accessible, which was a key criterion in  Grunewald et al. (2017)  or available through data sources that are backed up by decision makers and involved experts. To tackle the problem of data availability, Niraj-MAES applied an iterative 'zooming in' approach for selecting the ES and their indicators with a constant eye to data and methods availability. Any ES indicator that seemed unfeasible to be modelled and mapped with the available data (and time and resources) was dropped. An alternative approach is the use of proxies, such as was done by the Finnish NEA. Time availability, both for developing and quantifying the indicator, also ultimately determines whether an assessment can be realistically carried out  (Brown et al.
, 2014). This is not only related to data availability, but also with project duration and with the existence of a post-project follow-up protocol, as processing data might take a long time or data updates might become available only at low frequencies. Time availability is also determined by how urgently the data is needed to make decisions about a problem they must solve. Tratalos et al. (2016)  mention that an additional criterion for their study included that there should be short time lag between the state of affairs measured and the indicator becoming available (UK NEA cultural ES). Another key criterion, although not yet often made explicit in our case studies, relates to whether ES indicator development and application is affordable or cost effective  (Brown et al. , 2014; Hauck et al.
Acknowledgements The work by AvO is funded by the  STW  research programme ' Nature-driven nourishment of coastal systems (NatureCoast) ' (grant number  12691 ), which is (partly) financed by the  Netherlands Organisation for Scientific Research (NWO). The work of IG, LC and CP was supported by grants from the  MAVA Foundation , the  Total Foundation , the  Prince Albert II of Monaco Foundation  and the  French Ministry of Ecology. The work by  CA, RS  and  KG  for  MAES Germany  was commissioned by the  Federal Ministry for the Environment, Nature Conservation, Building and Nuclear Safety (Environment Ministry, BMUB)  and the  Federal Agency for Nature Conservation (BfN). Niraj-MAES  was supported by the  EEA Financial Mechanism  and the  Romanian Ministry of Environment, Forests and Waters  under the project " Mapping and assessment of ecosystem services in Natura 2000 sites of the Niraj-Tarnava Mica region " ( Programme RO02 , grant No.
3458/19. 05. 2015 ). The work by  AL  and AN was supported through the  AQUACROSS  project funded by the  European Union 's  Horizon 2020 Programme for Research, Technological Development and Demonstration  under Grant Agreement no. 642317. Thanks are also due, for the financial support to CESAM ( UID/AMB/50017/2013 ), to FCT/MEC through national funds, and the co-funding by the  FEDER , within the  PT2020 Partnership Agreement and Compete 2020. The work of LM was supported by  MAES   Finland  project that is funded by the  Ministry of the Environment, Finland. The work of MP-R was financed by the  Spanish Ministry of Education  through a  University Teacher Training grant. The work by JT was carried out at the  University of Nottingham  and funded under the National Ecosystem Assessment Follow-on (NEAFO) programme.
Electrochemical Measurements Polarization curves were carried out using a conventional three electrodes cell set-up at room temperature, 25 • C, in a potentiostat model 1287 SOLARTRON (Farnborough, UK) and software CORRWARE 2. The working electrodes (WE) with 1 cm 2 area were the 63. 5Fe25Cr7Ni4. 5B samples processed by melt-spinning, HVOF, and spray forming. For comparison reasons, the AISI 1045 steel substrate for HVOF and spray deposition and the SAF 2205 base alloy were also used as WE. The counter electrode was a platinum (Pt) sheet, and a saturated calomel electrode (SCE) was used as the reference electrode. Electrochemical measurements were performed in chloride-rich acid (pH = 3. 0), neutral (pH = 5. 5), and alkaline (pH = 10. 0) solutions containing 35 g/L of NaCl, typical of marine environments.
In this case, the solutions were prepared by using deionized water and additions of H 2 SO 4 and NaOH to adjust the pH of acid and alkaline electrolytes, respectively. Before the analysis, the solutions were subjected to air bubbling for 30 min to assure oxygen saturation. Potentiodynamic polarizations, with a scan rate of 1 mV/s, were launched after 30 min of immersion of the sample in the solution to allow steady free potential conditions to be reached. Corrosion current density (i corr ) and the corrosion potential (E corr ) were used to evaluate the corrosion behavior of the as-spun ribbons, HVOF coatings, and sprayed deposits. The i corr was determined by extrapolating the anodic and cathodic Tafel regions around E corr. Reproducibility of data was verified by repeating the test three times.
Materials and methods This systematic review was performed in accordance with the preferred reporting items for systematic reviews and meta-analyses guidelines. 23 ta sources and research strategy Two major electronic databases were searched: PubMed and Google Scholar. Clinical trials were also identified through the International Clinical Trials Registry Platform search portal (available at http://apps. who. int/trialsearch/). The research strategy (Table  S1 ) combines both keywords related to plasma (e. g. 'plasma discharge' or 'atmospheric plasma') and keywords related to medical fields (e. g. tumor, oncology). This strategy was then slightly adapted to meet requirements of each database. Reference lists of query studies were inspected to identify any additional relevant published or unpublished data.
Acknowledgements Study concept and design: AD, PM, SL, FV, JPS, NM, SC. Acquisition of data: AD, PM, SL, SC. Analysis and interpretation of data: AD, PM, SC. Drafting of the manuscript: AD, PM, SC. Administrative, technical and material support: SL, FV, JPS, NM, SC. Study supervision: PM, SL, FV, JPS, NM, SC. All of the named authors were involved in the paper and have read it before being submitted for publication.
CAD-CAM Manufacturing Procedures (Groups 1 and 2) The CAD-CAM manufacturing for both zirconia and LD was done with the CARES System (Straumann, Basel, Switzerland). Each master cast was precisely positioned in the holder of the scanner according to the manufacturer's indications and the scanning output was carefully verified. The CAD process was differentiated according to the material to be used according to the specifications of the dedicated software (CARES Visual 6. 2). The CAD of the copings started by choosing the most appropriate shape of the entire final crown from an anatomic library. Then, a uniform layer was virtually cut back from the outer surface of the crown, resulting in an improved customized coping design to provide adequate support to the veneering ceramics. The CAD file was sent to a centralized milling center to complete the CAM procedures and the copings were received after 5 working days.
Precision of Fit and Micro-Computed Tomography (Micro-CT) Analysis The median sections in the coronal (mesial-distal direction) and sagittal (buccal-palatal direction) planes of each specimen were identified by means of a micro-CT scanning (Skyscan 1072, Bruker, Kontich, Belgium) and analyzed in a dedicated software (NRecon 1. 6. 6. 0, Bruker) for the evaluation on marginal and internal fit. Eighteen measuring locations (9 per section) were used to evaluate the cement thickness in µm along the entire preparation, in order to assess both the marginal opening and the internal fit of the crowns  [22]  (Fig. 2 , Table  1 ). The measurements were obtained in µm from each surface of the specimens, particularly from the buccal and palatal surfaces in the sagittal section and from the mesial and distal surfaces in the coronal section; the measuring locations were summarized in Table  1.
Each tooth was scanned using micro CT (SkyScan 1072, Bruker) with the following settings: 10 W, 100 kV, 98 mA, a 1 mm thick aluminum plate, 15x magnification, 4. 9 s exposure time and 0. 45° rotation step. The acquisition procedures consisted of the creation of several 2D lateral projections of the specimens during a 180° rotation around the vertical axis. The digital data were elaborated using a reconstruction software (NRecon 1. 6. 6. 0, Bruker), which provided new axial cross-sections with a pixel size of 19. 1x19. 1 µm; the distance between each cross-section was 38. 0 µm and the cross sections were collected for each sample. The pixel-micron conversion ratio and the cross-section distance were set in measurement tools included in a dedicated software (Mimics 12. 1, Materialize, Leuven, Belgium), thus areas and volumes were calculated.
Images were acquired from 972 slices of each tooth. After cone beam reconstructions, the raw data were converted into 16-bit dynamic grayscale picture files with a 2000x2000 pixel bitmap (BMP) format and saved in a specific program (Skyscan Data Viewer 1. 4. 4, Bruker) to complete the reconstructions. The cementation areas were reconstructed three-dimensionally and a semiautomatic threshold-based segmentation approach was combined with manual editing of slices. Two calibrated investigators, who had been blinded with regard to the experimental groups, independently measured the precision of fit of the specimens. The measurements were repeated 3 times and the values averaged. Intraexaminer reliability was assessed by the Kappa test (K=0. 88).
Statistical Analysis The data were statistically analyzed using a statistical software (SPSS 16. 0, SPSS Inc. , Chicago, IL, USA). Due to the pooled data set of cement thicknesses measured in the 3 groups at different levels, the adaptation values at measuring locations were analyzed by means of One-Way Analysis of Variance (ANOVA) followed by the Tukey's test for post-hoc comparisons as needed, in order to compare cement thicknesses at different levels within the same group and between different groups at the same level. The absolute marginal opening was calculated as the sum of the measurement locations MG1-2 and FL1-2 while the internal fit was calculated as the sum of the measurement locations AW1-2, BC, OCF and LC. In all the statistical analyses, the level of significance was set at p<0.
It was suggested to replace DXP/PC by another step 2 analgesic, e. g. tramadol or codeine, and by PC for weaker pain level  [8]. While the consequences of DXP/PC withdrawal on suicidal deaths have been studied  [9] [10] [11] [12] [13] [14] [15] , its effect on overall analgesic prescriptions have been little investigated  [3]. Due to their specific benefit/risk ratios and their extensive use, drugs replacing DXP/PC have impacted the management of pain, and the quality of care. These changes need to be detailed, first of all in terms of use of analgesics. To provide a first set of data, an analysis of the Rhône-Alpes URCAM (Regional Union of Health Insurance Fund) database with 5 million inhabitants covered by the general health insurance scheme was performed, to describe analgesics dispensation between 2009 and 2012, around the time of DXP/PC withdrawal.
Analysis of analgesic dispensations To investigate DXP/PC replacement, dispensation data of all prescribed analgesics were requested for the period January 2009 to December 2012 for the Rhône-Alpes region of France. The regional fund that is part of the national health insurance system  [16]  provided a dataset containing records of all analgesics that had been dispensed during that period to patients covered by the general health insurance scheme (i. e. 80% of the regional population). This extraction was based on CIP code (specific national identification code of medicinal products) of all analgesics (Table  1 ). The aggregated number of packs monthly dispensed was computed (in France drugs are sold as indivisible units). For the analyses, the Anatomical Therapeutic Chemical classification/defined daily dose (ATC/DDD) methodology of the WHO Collaborating Centre for Drug Statistics Methodology was used  [17].
The dispensation of oral analgesics was described over time by DDDs/1000 inhabitants/day. The changes of DDDs between January-June 2009 and January-June 2012 for each analgesic step were computed by subtracting the numbers of DDDs/1000 inhabitants/day of each medicinal product reimbursed during the prewithdrawal period (Jan-June 2009) from the numbers of DDDs reimbursed during the post-withdrawal period (Jan-June 2012), divided by the total numbers of DDDs reimbursed during the pre-withdrawal period. All analyses were performed using SAS software, version 9. 4 (SAS Institute Inc. , Cary, NC, USA).
As we discuss later, due to the high junction energy, the transition requires a step of nucleation. Kinetics data are not conclusive to provide time scales of the transitions. We rather show that the intermediate state exists on the path of the B-Z transition as a thermodynamic state. The existence of the third, intermediate state is further supported below. To gain insight into the origin of the intermediate FRET signal, we performed CD measurements. We tested the same core molecules bearing a 6-bp flanking sequence at each end ((GC) 11 and (TG) 11 ) as those to be ligated to a PCR fragment for smFRET assays. = 10 M, the CD spectrum around 290 nm appears flat (ellipticity ∼ 0) for (TG) 11. This near flatness of CD spectrum should result from linear superposition of two spectra with opposite helicities (right and left).
Bishop's data We compared the above wavelet versus the data published by Bishop  [2]. The neural mechanisms have been studied by this author in the striate cortex of the cat. A stereopair of lines was viewed in a stereoscope. The two retinal images, XRYR (right eye) and XLYL (left eye) were at an angle to one another. The position disparity was deduced to the length of the line YLYR. The angle between the two images was the orientation disparity. The orientation and position disparity changes occurred in the right eye with the left eye image held constant. The position and orientation disparities were expressed in terms of a visual angle. The data given by Bishop  [2]  are represented by the points in Fig. 5a  and 5b. The angle  was the orientation disparity for the right eye. The left eye image held constant at 93°.
Introduction Many fields in astrophysics, especially the modelling of various stellar atmospheres and the kinetics of stellar and other astrophysical plasmas, depend on data for atomic and molecular collisions  [1] [2] [3] [4] [5] [6]. Modern codes for stellar atmosphere modelling (e. g. ,  [7, 8] ) require knowledge of atomic data, so the accuracy of these data becomes very important. Among these data there are atomic and molecular processes and spectral regions that even today are poorly investigated. Therefore, there is a need for further investigation and development of methods for improving the existing ones  [9] [10] [11]. Recently, the research community has become aware of the need for better atomic data which could be important in modelling of AGN BLR clouds  [12]. In this paper we analyze the current state of research on ionisation (chemi-ionization) processes and excitation and de-excitation ((nn )-mixing) processes in collisional reaction A * (n) + A involving hydrogen and helium atoms.
DNA extraction was performed as previously described  (Stukenbrock et al. 2011). Library preparation and paired-end sequencing using an Illumina HiSeq2000 platform were conducted at Aros, Skejby, Denmark. The 13 resequenced Z. ardabiliae genomes were assembled from 100-bp, paired-end reads using the de novo assembly algorithm of the CLC Genomics Workbench version 5. 5  (QIAGEN, Aarhus, Denmark). The assemblies were created using standard settings for paired-end reads. We used a previously published RNA-sequencing-based annotation to distinguish the parameter estimates for coding and noncoding sequences  (Grandaubert et al. 2015). To predict the genes that encode effectors, we used the software EffectorP  (Sperschneider et al. 2016) , with default settings, on genes predicted by SignalP  (Petersen et al.
Genome alignment and SNP calling Genome alignments were separately created for each population using the MultiZ program from the TBA package  (Blanchette et al. 2004). Default parameters were used, although LastZ was used instead of BlastZ for pairwise alignments. Genome alignments were projected against the two reference genomes of each species: IPO323 for Z. tritici and STO4IR-1. 1. 1 for Z. ardabiliae  (Goodwin et al. 2011; Stukenbrock et al. 2011). The projected alignments in MAF format were filtered using the MafFilter program  (Dutheil et al. 2014)  with the following filters: (1) each syntenic block was realigned using MAFFT  (Katoh et al. 2009) , and blocks with. 10 kb were split for computational efficiency; (2) only blocks where all individuals were present were retained (13 Z. tritici and 17 Z.
ardabiliae); (3) a window of 10 bp was slid by 1 bp, and windows containing at least two indel events were discarded and the containing blocks were split; (4) a window of 10 bp was slid by 1 bp, and windows with a total of. 100 gap characters were discarded and the containing blocks were split; and (5) all blocks were merged according to the reference genome with empty positions filled by "N," which resulted in one masked alignment per chromosome for Z. tritici and one masked alignment per contig for Z. ardabiliae. The chromosome and contig alignments were further divided into nonoverlapping windows of 1 Mb (data set 1) or 100 kb (data set 2). The MafFilter program was further used to estimate statistics on the alignments at each filtering step, and to compute the nucleotide diversity (Watterson's u) from the final filtered genome alignments.
Estimating recombination Filtered alignments (1-Mb windows, data set 1) were exported as fasta files for the LDhat and LDhelmet packages. The program "convert" from the LDhat package was used to convert fasta files into input loci files for the program "interval"  (Auton and McVean 2007). Only fully resolved biallelic positions were exported (see Table  1  for the details of SNP numbers). Likelihood tables were generated for u values of 0. 0005, 0. 005, and 0. 05. The interval program was run with 10,000,000 iterations and sampled every 5000 iterations with a burn-in of 100,000 iterations. LDhelmet was run with the parameters suggested in the user manual  (Chan et al. 2012 ; https://sourceforge. net/ projects/ldhelmet/). Comparison of recombination maps on the same set of SNPs was performed using standard principal component analysis, as implemented in the R package ade4  (Dray and Dufour 2007).
Pairs of SNPs for which the confidence interval of the recombination estimate was higher than two times the mean were discarded and therefore not used in the average computation. Using the gene annotations available for the two reference species  (Grandaubert et al. 2015) , we calculated the following information for each gene: (1) the average recombination rate in exons, (2) the average recombination rate in introns, (3) the average recombination rate in the 500 bp flanking the 59 region, and (4) in the 500 bp flanking the 39 region. We also calculated the average recombination rate for each intergenic region (500 bp from/to genes). GFF3 files from  Grandaubert et al. (2015)  were retrieved and processed using the GenomeTools package to add intron annotations  (Gremme et al. 2013). The resulting gene annotations were analyzed in R together with recombination maps (R Core Team 2013).
The true recombination rate used at each position of the alignment was recorded for later comparison. The output of SCRM was converted to LDhat input format using Python scripts. Recombination rates were estimated using the interval program from the LDhat package  (Auton and McVean 2007). For simulations with u = 0. 05 and 0. 005, a likelihood lookup table with u = 0. 01 was used; whereas a lookup table with u = 0. 001 was used for simulations with u = 0. 0005 and 0. 00005. The inferred recombination rate at each position was then compared to the true rate. A variant of this simulation procedure was used to assess the impact of population structure on the inference of recombination rate. The SCRM coalescent simulator was used with a five-islands population model, with sample sizes of 2, 3, 4, 5, and 6 per deme, resulting in a total of 20 individuals.
Because recombination rates are typically exponentially distributed, Pearson's coefficient was measured for the log rates instead of the raw r rates. Spearman's coefficient assumes that the variables are continuously distributed; therefore it does not resolve ties. Thus "jittering" was used to randomly resolve ties in the input variables (R function jitter, with default parameters). Conversely, Kendall's coefficient assumes ordinal input variables. Therefore, using the three correlation measures allows assessing the robustness of the correlation signal. A graphical representation was performed using the ggplot2 package for R, which performed local polynomial regression fitting for the curves  (Wickham 2016).