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\fancyhead[RE,LO]{\bf Estimate $\mathbi{N}_0$}%
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\cfoot{--- Andreas Suter -- \today ---}
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\begin{document}

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\noindent
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\noindent\includegraphics[width=3.4cm]{PSI_Logo_narrow_blau.jpg} &
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Datum:   & \today        &     & \\[3ex]
Von:     & Andreas Suter & An: & \\
Telefon: & +41\, (0)56\, 310\, 4238        &     & \\
Raum:    & WLGA / 119    & cc: & \\
e-mail:  & \verb?andreas.suter@psi.ch? & & \\
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\noindent The \musr decay histogram can be described by

\begin{equation}\label{eq:decay}
 N(t) = N_0\, e^{-t/\tau_\mu} \left[ 1 + A P(t) \right] + \mathrm{Bkg}
\end{equation}

\noindent For single histogram fits a good initial estimate for $N_0$ is needed
in order that \textsc{Minuit2} has a chance to converge.
Here I summaries how $N_0$ can be reasonably well estimates. For all estimates,
it is assumed that rather to take Eq.(\ref{eq:decay}), 
the following ansatz will be used

\begin{equation}\label{eq:N0ansatz}
 T(t) = N_0\, e^{-t/\tau_\mu} + \mathrm{Bkg},
\end{equation}

\noindent \ie the asymmetry is ignored all together.


\section*{Estimate $\mathbi{N}_0$ with free Background}

We would like to minimize $\chi^2$, which is

\begin{equation}\label{eq:chisq}
 \chi^2 = \sum_i \frac{(D_i - T_i)^2}{\sigma_i^2} = \sum_i \frac{(D_i -
T_i)^2}{D_i},
\end{equation}

\noindent where $D_i$ is a histogram entry of the measured data, $T_i$ the
evaluation of Eq.(\ref{eq:N0ansatz}) at $t_i = \Delta t \cdot i$, with $\Delta
t$ the histogram time resolution. In the last step Poisson statistics is used,
\ie $\sigma_i^2 = D_i$.
In order to minimize Eq.(\ref{eq:N0ansatz}), it is sufficient that $\nabla
\chi^2 = 0 \Longrightarrow$

\begin{eqnarray*}
 \frac{\partial \chi^2}{\partial N_0} &=& \sum_i \left[ \frac{2 (D_i -
T_i)}{D_i}\, e^{-t_i/\tau_\mu} \right] = 0 \\
 \frac{\partial \chi^2}{\partial \mathrm{Bkg}} &=& \sum_i \left[ \frac{2 (D_i -
T_i)}{D_i} \right] = 0 
\end{eqnarray*}

\noindent With the following abbreviations

\begin{eqnarray}\label{eq:abbrv}
  x_i &=& e^{-t_i/\tau_\mu} \\
  \Delta &=& \sum_i 1/D_i \nonumber \\
  S &=& \sum_i 1 \nonumber
\end{eqnarray}

\noindent ($S$ is the number of bins in the histogram) the background can be
written as

\begin{equation}\label{eq:bkgEstimate}
 \mathrm{Bkg} = \frac{1}{\Delta}\, \sum_i \left[ 1 - \frac{N_0}{D_i}\, x_i
\right]
\end{equation}
 
\noindent and using this result, $N_0$ is

\begin{equation}\label{eq:N0estimate}
 N_0 = \frac{\displaystyle\sum_i \left[x_i \left(1-\frac{S}{D_i
\Delta}\right)\right]}{\displaystyle\sum_j \left[\frac{x_j}{D_j}\left(x_j -
\frac{1}{\Delta} \sum_k \frac{x_k}{D_k}\right)\right]}.
\end{equation}

\noindent Eqs.(\ref{eq:bkgEstimate}) \& (\ref{eq:N0estimate}) allow to estimate
$N_0$ and Bkg. However, the results are mostly unsatisfactory since typically
$N_0$ is underestimate whereas Bkg is grossly overestimated. The reason is the
missing asymmetry term.

\section*{Estimate $\mathbi{N}_0$ with linked Background}

A much more robust ansatz is to link the background to $N_0$, \ie

\begin{equation}\label{eq:N0ansatz_with_linked_bkg}
 T(t) = N_0\, e^{-t/\tau_\mu} + \mathrm{Bkg} = N_0\, e^{-t/\tau_\mu} + \alpha
N_0,
\end{equation}

\noindent where $\alpha$ is typically $0.01$ are smaller. The practical tests
show that it is mostly save to set $\alpha=0$. From 

$$ \frac{\partial \chi^2}{\partial N_0} = 0 $$

\noindent it follows

\begin{equation}\label{eq:N0estimate_with_linked_bkg}
 N_0 = \frac{\displaystyle\sum_i (\alpha +
x_i)}{\displaystyle\sum_i\frac{(\alpha + x_i)^2}{D_i}}.
\end{equation}

\noindent Eq.(\ref{eq:N0estimate_with_linked_bkg}) with $\alpha < 0.01$ leads typically to
very good results.

A closer look at Eq.(\ref{eq:N0estimate_with_linked_bkg}) reveals that there is
a principle problem. How should one deal with $D_i = 0$? There are two
possibilities:

\begin{enumerate}
 \item if $D_i = 0$, set it to $D_i = 1$. This implicitly assumes that an empty bin has an uncertainty of 1.
 \item if $D_i = 0$, ignore it!
\end{enumerate}

\noindent Currently \texttt{musrfit} ignores empty bins.

\end{document}