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Therefore, minor contamination levels (C) of each cancer sequencing data were estimated as below: C = 2 × ∑ (R C w t ) − N e ∑ (R D h o m ) − N e, where RD hom is sequencing read depth, RC wt is read-count of wild-type alleles, and Ne is number of sequencing errors on each autosomal homozygote SNP site.
Waste data were estimated (as discussed in Lenzen and Reynolds 2014 and Reynolds 2013), with only formal disposal accounted for.
The picking errors of P- and S-wave arrival times for the high-sampling data were estimated as 2 and 30 ms, respectively (Doi et al. 2013), which indicates very high accuracy, whereas the picking errors of P-wave arrival times for the Manten observation were slightly larger because of the lower sampling rate of 250 Hz.
Thresholds for cbs-smoothed data were estimated as described previously [ 65].
For example, the parameters of the probabilistic model for Nanog TF data were estimated as θ = 0.997; α = 5.870; β = 7.465, and thus, from (28), we have p0 = 0.22.
Expression data were estimated as the average of normalized intensity signal values of replicates, and comparisons between F2 bm3 or AS225 with the normal F2 line were based on expression value ratios.
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Signal to Noise ratio analysis on Ca2+ response to ATP titration data was estimated as was done previously (Selimkhanov, 2014).
Radiation data are estimated as either 1-h or 24-h values.
For schools with data missing for only one of the four years, the year of missing data is estimated as the average debt of the three other years for which data is available.
The diploid coverage of the WGS data was estimated as the percentage of heterozygous sites detected using genotyping that were also heterozygous in the sequence data.
The within contemporary group minor allele frequency for pooled data was estimated as the mean of the allele frequencies of the pools, weighted by the number of individuals in each pool.
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